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Vol.:(0123456789)
1 3
Environmental Science and Pollution Research
https://doi.org/10.1007/s11356-022-20079-3
APPLIED ECONOMICS OFENERGY ANDENVIRONMENT INSUSTAINABILITY
Impact ofenergy efficiency, technology innovation, institutional
quality, andtrade openness ongreenhouse gas emissions inten Asian
economies
ZhengWenlong1· NguyenHoangTien2· AmenaSibghatullah3· DaruAsih4· MochamadSoelton4· YantoRamli4
Received: 23 October 2021 / Accepted: 31 March 2022
© The Author(s), under exclusive licence to Springer-Verlag GmbH Germany, part of Springer Nature 2022
Abstract
Despite the fact that Asian economies have experienced robust economic growth in recent decades, rising pollution emissions
have raised worries among policymakers about the long-term stability of this output growth. Knowing this fact, the present
study attempts to empirically analyze the impact of some important factors, e.g., energy efficiency, technology innovations,
trade openness, and institutional quality, on environment in 10 Asian economies over the period 1995–2018. Taking into
account the slope heterogeneity and cross-sectional dependence present in the data, Westerlund and Edgerton (2008) and
Banerjee and Carrion-i-Silvestre (2017) cointegration techniques and cross-sectionally augmented autoregressive distributed
lag model (CS-ARDL) estimation are applied. For robust analysis, augmented mean group (AMG) and common correlated
effects mean group (CCEMG) are also employed in the study. The empirical findings provided by selected variables reveal
that both trade openness and institutional quality have detrimental impact, whereas energy efficiency and technology inno-
vations have favorable impact on environmental quality in the selected economies. Empirical findings are robust to various
policy recommendations. To create a sustainable future environment, Asian economies should focus on the improvement
of their institutions quality and increase investments in technology innovations. The Asian countries must encourage trade-
related environmental regulations and energy efficiency policies for better and sustainable environmental quality.
Keywords Energy efficiency· Technological innovations· Trade openness· Institutional quality· GHG emission
Introduction
The most prominent environmental concern faced by
the international community has been greenhouse gas
emission (GHG emission) which is a key determinant of
environmental hazards such as climate change and global
warming (Alola, 2019). Carbon dioxide gas which is mostly
derived from fossil resources causes 76% of total GHG emis-
sions and is widely acknowledged as the most significant
environmental pollutant. In this context, GHG emissions
continue to pose a serious risk to the human lives and the
environment. Because of the global warming induced by
Responsible Editor: Roula Inglesi-Lotz
* Nguyen Hoang Tien
nguyenhoangtien@siu.edu.vn
Zheng Wenlong
1556236510@qq.com
Amena Sibghatullah
amena@kiet.edu.pk
Daru Asih
daru_asih@mercubuana.ac.id
Mochamad Soelton
soelton@mercubuana.ac.id
Yanto Ramli
yanto.ramli@mercubuana.ac.id
1 School ofEconomics andManagement, Chang’an
University, Middle-section of Nan’er Huan Road Xi’an,
Xi’an710064, ShaanXiProvince, China
2 Saigon International University, HoCHiMinhCity, Vietnam
3 College ofManagement Sciences, KIET University, Karachi,
Pakistan
4 Universitas Mercu Buana, Jalan Meruya Selatan No. 1,
Meruya Selatan, Kembangan, Jakarta, Indonesia
Environmental Science and Pollution Research
1 3
GHG emissions, countries have taken actions to minimize
these emissions by addressing energy efficiency regulations
in recent decades (Akdag & Yıldırım, 2020; Zhuang etal.,
2021). Countries all over the world have continued to look
for environmentally friendly sources of energy like “renewa-
ble energy” and alternate sources. The importance of energy
efficiency and technological innovation has grown in recent
years as a result of their potential to reduce environmen-
tal damage and cost saving (Akdag & Yıldırım, 2020; Sun
etal., 2020). Energy efficiency means using lesser energy
to produce the same amount of goods and services. Numer-
ous advantages might be gained by increasing investment in
energy efficiency. Energy efficiency measures, for example,
can help to improve ecosystem sustainability, reduce envi-
ronmental impact by lowering CO2 emissions, reduce fossil
fuel dependence, and stimulate industrial rivalry by lowering
operational costs (Akram etal., 2020b). The global climate
change can be combated by energy efficiency in two ways.
First, “The lesser the energy utilized, the lower the amount
of emissions released.” It suggests that efficiency in energy
has a significant contribution in energy policies for future
programs and climate change. Secondly, energy efficiency
that is cost-effective accomplishes these environmental
advantages at a low cost lowering the economic costs of
attaining climate policy goals (Javid & Khan, 2020). Fur-
thermore, energy efficiency is a key component of the green
development plans of the countries which aim to minimize
emissions by improving energy efficiency (Akram etal.,
2020b; Shair etal., 2021; Zhao etal., 2021). Furthermore,
meeting the Sustainable Development Goals necessitate the
increased use of energy efficiency. Regardless of its impact
on GHG emissions, energy efficiency has numerous public
advantages too. It lowers energy costs for businesses, boosts
productivity and economic growth, improves energy secu-
rity, reduces prices of energy, and mitigates air pollution
emissions (Nawaz, etal., 2021a, b).
Several earlier studies (e.g., Goulder & Mathai, 2000;
Hasanbeigi etal., 2012; Santra, 2017) identified that adop-
tion of modern technology has the ability to minimize GHG
emissions as it improves energy efficiency without affecting
economic development. Environmental technology measures
may have two effects on GHG emissions. At one side, they
influence carbon-based fuel pricing by implementing taxes
that effectively minimizes consumption of energy and pollu-
tion emissions, and on the other side, these policies incentiv-
ize companies to acquire or develop new technologies to get
alternative fuels with lower carbon emissions. However, it is
argued that the technological advancements add to resource
depletion and environmental damage through the rebound
effect. Industrial sector technology tends to enhance produc-
tion activities which necessitate additional raw materials and
resources of energy and compromises environmental quality
(Greening etal. 2000; Khan etal. 2017). However, there is
limited empirical work available indicating the link between
technology innovations and GHG emissions, and this study
is an addition to the existing literature by estimating whether
or not innovations help to mitigate GHG emissions (Amin
etal. 2020; Mohsin etal. 2021).
The environmental impacts of trade openness have also
been a hot topic of research in recent years. Empirical stud-
ies suggest that free trade policies may result in shifting
pollution-intensive items or “dirty goods” production from
industrialized to underdeveloped countries (Ansari etal.,
2019; Salahuddin etal., 2018; Shahbaz etal., 2013). The
expansion of liberated trade and the relocation of polluting
item industries from one region to others are causing envi-
ronmental issues. Despite the fact that poor countries have
increased their emissions in recent years, rich countries have
historically been the source of a major percentage of world
emissions. In general, it is unclear whether cross-national
free trade causes environmental degradation or not. Trade
affects the environment depending upon its three effects on
an economy, namely, composition effect, scale effect, and
technological effect. According to scale effect, the produc-
tion scale and economic growth level are increased by the
trade resulting in higher GHG emissions due to increased
output and energy consumption. According to the prin-
ciple of comparative advantage when the trade composi-
tion matters, especially when demand for dirty items rises
output rises at the same time. Finally, the technique effect
suggests that trade increases competitiveness, efficiency,
and environmentally beneficial technology, all of which
reduce GHG emissions. Hence, trade can have a favorable
or harmful impact on GHG emissions depending on the rela-
tive magnitude of these three effects (Ansari etal., 2020).
Moreover, with the increased acknowledgment of the institu-
tions, institutional quality indicators have just begun to be
integrated into environmental sustainability studies. In this
context, institutional factors, e.g., voice and accountability,
government effectiveness, democracy, law, political stabil-
ity, corruption, bureaucratic quality, and regulatory quality,
have been extensively studied as the impact of institutional
quality on issues related to environment particularly carbon
and other pollutant emission. It is evidenced that market fail-
ures can be avoided, effective regulations can be generated,
and sound environmental policies can be planned with well-
performing institutions, all of which can have a significant
impact on environmental stability (Li etal., 2021; Riti, Shu,
& Kamah, 2021).
Taking into consideration the above-mentioned argu-
ments, the study aims to estimate the impact of technol-
ogy innovation, institutional quality, energy efficiency,
and trade openness on GHG emissions in a panel of ten
Asian economies (India, Indonesia, China, Malaysia,
Philippines, Pakistan, Singapore, Sri-Lanka, Thailand,
and Vietnam) over 1995–2018 period. To the author’s
Environmental Science and Pollution Research
1 3
knowledge, no attempt has been made to evaluate the rela-
tionship between these variables in a single framework
across Asian countries. Asia is a well-known region of the
largest economies of the world, accounting for more than
half of the global population. The decision to study Asia is
also influenced by the fact that it accounts for 28% of the
global energy demand and 53% of the total coal consump-
tion of coal, both of which are significant sources of GHG
emissions (Amin etal., 2020). This region contributes to
half of the global CO2 emission. The Republic of Korea,
China, India, and Singapore are among the top greenhouse
gas–emitting countries in the world. South Korea, Japan,
Malaysia, and China are among the top trading economies
in the world. India, Pakistan, China, and Japan are among
the most populous countries in the world. China, as one
of the world’s fastest-growing economies, has seen a mas-
sive increase in energy consumption, as well as a massive
increase in greenhouse gas emissions over the last three
decades (Chien etal., 2021a, 2021b; Saleem etal., 2020).
Thus, our study focuses on the relation between technol-
ogy innovation, energy efficiency, institutional quality,
trade openness, and GHG emissions in such a highly emit-
ting and fast-growing region and helps policymakers to
employ efficient policies for environmental sustainability
in these countries. Hence, the foremost objective of the
study is to check to what extent the technology innova-
tion control GHG emissions. The objectives also include
examining energy efficiency role in reducing GHG emis-
sions. In addition, the investigation of the institutional
quality impact on GHG emission is also part of the study
objectives. Finally, the objective of the study includes the
investigation of trade openness impact in reducing GHG
emission.
The remaining sections of the study are structured as
follows: the “Literature review” section gives the existing
literature review. The “Econometric methodology and data
sources” section provides the description of the variables
and the methodology employed for empirical analysis. The
“Empirical results” section outlines the empirical findings
of the analysis. Last, conclusion of the study and some
policy recommendations are given in the “Discussions”
section.
Literature review
For the past few decades, extensive research has been car-
ried out on the relationship between technology innovations,
trade openness, quality of institutions, energy efficiency, and
environmental quality both for emerging and developed
countries. We will go through a few key researches from
the current literature in this section. Apart from that, we also
discuss the influence of our selected variables on a country's
environmental quality.
Technological innovations–environment nexus
Technological innovations have been introduced as a new
determinant in the environmental studies recently because
it is acknowledged as a significant mitigating factor of pol-
lutant emissions globally (Chien, etal., 2021a, b, c, d, e;
Nawaz, etal., 2021a, b). In existing literature, many studies
have found an association between quality of environment
and technological innovations. For example, Long etal.
(2018) analyzed how innovations affected carbon emis-
sions in China over the 1997–2014 period. The researcher
concluded that innovations had an adverse impact on CO2
emissions and a contribution to improve the environmental
quality (Long etal., 2018). In a study of Malaysia, Yii and
Geetha (2017) tried to study the link between carbon dioxide
emission and technology innovation. Using the data from
1971 to 2013, authors concluded that technology innova-
tion had negative influence on carbon dioxide emission in
Malaysia (Yii & Geetha, 2017). The study of Dauda etal.
(2021) in the context of nine African economies concluded
that innovations increased the CO2 emissions, but square
of innovations reduced it for the whole panel. However, the
inverted U-shaped relation of innovation and CO2 emissions
was found only in Egypt, South Africa, Morocco, and Mau-
ritius (Dauda etal., 2021). In the same vein, Hodson etal.
(2018) studied the energy division of the USA and estab-
lished that innovations declined carbon dioxide emissions
by providing efficient energy usage and cost-efficient way
of producing lesser carbon (Hodson etal., 2018).
The purpose of the study of Cheng etal. (2021) was to
see how energy technology innovation affected CO2 emis-
sion in China over 2001 to 2016 period. It was found that
energy technology innovations contributed to intensity of
carbon emission in lower quantile areas but reduced it in
higher quantile areas (Cheng etal. 2021). Using STRIPAT
and EKC theoretical frameworks, Hao etal. (2021) analyzed
the effect of economic growth and technology innovations
on the environment in 25 underdeveloped Asian economies
for 1998–2019 period, and the results of their study indi-
cated that technological innovations and economic growth
reduced carbon emission and protected environment. Moreo-
ver, it was also confirmed that EKC hypothesis existed in
the Asian economies under study (Hao etal. 2021). Omri
and Hadj (2020) researched the effect of governance, for-
eign investment, and technology innovation on CO2 emis-
sions in twenty-three emerging economies over 1996–2014
period. The findings of GMM estimation also revealed that
technology innovations had a significantly negative impact
on emissions (Omri & Hadj 2020). Similar researches were
Environmental Science and Pollution Research
1 3
conducted by Shahbaz etal. (2020) and Khan etal., 2020a,
2020b).
Technological innovations, on the other hand, were
found to accelerate the process of CO2 emissions also in
some studies. For instance, Ganda (2019) estimated the
effect of innovations on CO2 emission in OECD nations
for 2000–2014 period, and a positive effect of technology
innovations on CO2 emissions was found (Ganda, 2019). Yu
and Du (2019) reached the same conclusion and suggested
that technological innovations had promoting impacts on
emission of carbon in the group with higher growth as com-
pared to the group with lower growth in China (Yu & Du,
2019). Erdoğan etal. (2020) analyzed the relation between
technology innovation and carbon emission in fourteen
countries over 1991 to 2017 period. Their findings showed
that technology innovation contributed to CO2 emissions in
construction sector (Baloch etal., 2021; Chien etal., 2021c;
Huang etal., 2021a; Erdoğan etal., 2020). Thus, the current
study has developed the following hypothesis:
H1: Technology innovation has a positive and significant
impact on GHG emission in developing countries.
Trade openness–environment nexus
Many countries have been able to trade across borders as a
result of globalization. Numerous prior studies have exam-
ined the effect of trade liberalization on the environment
over time. The empirical researches, to be more exact, pro-
duce contentious results. The major conclusions of most
of the studies were that increased trade between coun-
tries pollutes the environment (Nasir & Rehman, 2011;
Ozturk & Al-Mulali, 2015). Some studies, on the other
hand, showed that increased trade between countries help
to reduce pollution levels (Dogan & Seker, 2016; Hos-
sain, 2011). For instance, Atici (2012) estimated how trade
affected carbon dioxide emissions for a sample of South
East Asian economies. It was indicated from the findings
that increase in exports increased CO2 emissions in the
selected economies (Atici, 2012). Shahbaz etal. (2014)
found that a relationship was existing between income,
trade liberalization, consumption of energy, and carbon
dioxide emissions by applying the ARDL technique and
consumption of energy and trade liberalization had a sig-
nificantly positive impact on carbon emission in the long
run. The results also indicated the validation of the EKC
hypothesis in Tunisia (Shahbaz etal., 2014). Similarly,
Al-mulali and Sheau-Ting (2014) researched the linkage
between consumption of energy, trade income, and carbon
emissions for 1990–2011 period. The findings showed a
significant positive relation between trade, energy usage,
and emission in the long run (Al-mulali & Sheau-Ting,
2014). Ertugrul etal. (2016) analyzed how trade open-
ness, real income, and consumption of energy affected
carbon emissions in the top 10 carbon-emitting develop-
ing economies over the period 1971–2011. Applying Zivot
Andrews unit root test and the VECM Granger causality
method, findings indicated that consumption of energy,
real income, and trade liberalization were the significant
determining factors of carbon emissions, and there existed
many fundamental relationships among the variables of
the study (Chien etal., 2021e; Ertugrul etal., 2016).
In the similar line, Zameer etal. (2020) and Huang
etal. (2021c) investigated the impact of technology inno-
vation, trade openness, FDI, economic growth, and energy
usage on carbon dioxide emissions in India over the period
1985–2017. The findings of VECM and ARDL bound test-
ing revealed that trade liberalization, usage of energy, and
growth affected CO2 emissions positively, whereas tech-
nology innovations and FDI affected CO2 emission nega-
tively. Moreover a bi-directional relationship was found
among innovation, energy usage, and trade openness in
the long run (Chien etal., 2021d; Huang etal., 2021b;
Tan etal., 2021; Zameer etal., 2020). In a recent work,
Tachie etal. (2020) explored the impact of trade open-
ness in EU 18 developed economies. Their findings indi-
cated that trade openness accelerated CO2 emission in EU
developed economies (Tachie etal., 2020). Likewise, Bal-
salobre-Lorente etal. (2018) analyzed the linkage between
CO2 emissions and growth in 5 EU economies (Germany,
France, Italy, Spain, and UK) over 1985–2016 period. The
findings showed that trade liberalization, consumption of
renewable electricity, and economic growth had a positive
effect on CO2 emission (Balsalobre-Lorente etal., 2018;
Sadiq etal., 2021a, b, c; Xiang etal., 2021; Xueying etal.,
2021). The study of Zhang etal. (2017) also indicated that
there was a significant negative impact of trade on carbon
emissions in ten developed economies (Zhang etal., 2017).
In contrast, Lv and Xu (2019) analyzed the relationship
between trade liberalization and environment using data
for fifty-five economies. Their findings revealed that trade
openness improved the quality of the environment in the
short run. But in the long run, trade openness had harmful
effects on environment (Lv & Xu, 2019). Using ARDL
approach, Ling etal. (2015) found that trade liberalization
improved the environmental sustainability for Malaysian
economy (Ling etal., 2015). Hasanov etal. (2018) and
Destek etal. (2018) revealed insignificant impact of trade
on carbon emission reduction (Destek etal., 2018; Hasa-
nov etal., 2018). Hence, the present article has established
the following hypothesis:
H2: Trade openness has a significant impact on GHG
emission in developing countries.
Environmental Science and Pollution Research
1 3
Energy efficiency–environment nexus
There appears to be dearth of literature about the nexus
between energy efficiency and GHG emissions so far.
According to the findings of Brookes (1990), energy effi-
ciency had a significant impact on economic growth. The
study concluded that energy efficiency improvements had a
favorable influence on growth but had no significant impact
on GHG emissions (Brookes, 1990). Wang etal. (2017) con-
ducted a study on the linkage between energy efficiency and
reduction of carbon emission in China and suggested that
carbon dioxide emission reduction methods as a means of
improving energy efficiency should be adopted. The studies
of Wang etal. (2017) and Emir and Bekun (2019) suggested
that energy efficiency was an important way to lessen con-
sumption of energy and global warming (Liu etal., 2021a;
Chien etal., 2021b; Ehsanullah etal., 2021; Emir & Bekun,
2019; Wang etal., 2017). Akdag and Yıldırım (2020) stud-
ied the linkage between efficiency in energy and GHG emis-
sions for 29 European countries and suggested the negative
link between energy efficiency and GHG emission as GHG
emission was found to be reduced by increase in energy effi-
ciency (Akdag & Yıldırım, 2020).
Chien etal. (2021b) analyzed how renewable energy and
energy efficiency affected carbon emissions in a panel of
Asian economies and found that a rise in renewable energy
and energy efficiency reduced carbon emissions in long
run, but in the short run, both strategies were effective
only for Nepal and India as indicated through heterogene-
ous coefficient estimates (Irfan etal., 2021). Akram etal.
(2020a, b) incorporated the effect of energy efficiency in
the construction of EKC hypothesis for a panel of 66 devel-
oping economies, and panel ordinary least squares and
fixed effect panel quantile regression revealed that energy
efficiency had an adverse impact on CO2 emission in all
quantiles but with varying degrees (Akram etal., 2020a).
Another study by Akram etal. (2020a, b) concluded that
positive shocks in renewable energy and energy efficiency
could significantly reduce CO2 emission in BRICS nations
(Akram, etal., 2020a, b; Chien etal., 2021e; Hsu etal.,
2021).
The study of Sathaye and Gupta (2010) was about the
function of energy efficiency in CO2 emissions reduction
for India by applying a scenario-based analysis. The results
concluded that in the year 2020, energy efficiency improve-
ments would likely to mitigate the CO2 emissions by sixty-
five million tons in India (Sathaye & Gupta, 2010). Another
scenario-based analysis by Chaturvedi and Shukla (2014)
also evidenced that energy efficiency improvements could
be a mitigating factor for the reduction of CO2 emissions in
India (Chaturvedi & Shukla, 2014). Lin and Ahmad (2017)
concluded that energy efficiency had massive potential to
mitigate carbon emissions in Pakistan (Lin & Ahmad, 2017).
Another study for Pakistan was conducted by Mahmood and
Marpaung (2014) to analyze the CO2 emissions reduction
impact of energy efficiency. The study found that energy
efficiency and the carbon tax had a remarkable impact on
CO2 emissions reduction in Pakistan (Mahmood & Mar-
paung, 2014). Thus, the current research has established the
following hypothesis:
H3: Energy efficiency has a positive and significant
impact on GHG emission in developing countries.
Institutional quality–environment nexus
In general, the views are divergent about the nexus
between institutional quality and environment. Some
of the researchers have observed a positive institutional
quality–environment relationship, while some studies
found that institutional quality accelerates environmental
degradation. For instance, Godil etal. (2020) estimated
the effect of institutional quality, financial development,
and ICT on carbon emission in Pakistan and concluded
that institutional quality contributed positively to CO2
emission (Godil etal., 2020). Azamet al. (2021) stud-
ied the effect of institutional quality on different envi-
ronment measures (CO2 and CH4 emission, area under
forest, water pollutants (organic), and energy consump-
tion) for 66 underdeveloped economies. The findings
of system GMM estimation indicated that institutional
quality had positive effect on CO2 emission, CH4 emis-
sion, and forest area (Azam etal., 2021). Huang etal.
(2021a)concluded that institutional quality had a positive
correlation with carbon dioxide emission and indicated
that bad governance, weak bureaucracy, corruption, and
improper execution of environmental laws led towards
environmental deterioration (Chien etal., 2021b; Othman
etal., 2020). For a panel of forty countries of SSA (Sub-
Saharan Africa), Ibrahim and Law (2016) studied what
role trade and institutional quality and the interactions
between both played in carbon emissions and found that
better institutional functioning was favorable to improve
environmental quality (Li etal., 2021; Huang et al.,
2021a, b, c; Liu etal., 2021b; Ibrahim & Law, 2016).
Incorporating other important determinants such as trade
liberalization, urbanization, development of financial
sector, and consumption of energy in underdeveloped
economies, a thorough analysis by Ali etal. (2019) to
estimate the effect of economic growth and quality of
institutions on environmental quality evidenced that the
pollution haven theory is refuted because well-function-
ing institutions could reduce environmental deteriora-
tion by suitably plighting polluted companies’ locations.
Furthermore, institutional action could help to improve
environmental deterioration through correct regulations
Environmental Science and Pollution Research
1 3
(Ali etal., 2019). Lee etal. (2021) analyzed the effect of
institutional quality and urbanization on GHG emissions
in the 48 BRI countries over the years 1984–2017 and
reported that although urbanization reduced the environ-
mental quality, the negative impact of urbanization could
be eliminated by improved institutional quality (Lee etal.,
2021). Similarly Muhammad and Long (2021) elaborated
that rule of law, political stability, and control of corrup-
tion played imperative role in carbon emission mitiga-
tion and improved the quality of environment in the BRI
countries (Muhammad & Long, 2021).
In contrast, there is the study of Chaudhry etal. (2021)
that established that institutional performance had nega-
tive impact on environment quality indicators in countries
of East Asia and Pacific specifically the high-income East
Asian and Pacific countries (Chaudhry etal., 2021). For
BRICS nations, Hussain and Dogan (2021) investigated the
effect of the quality of institutions and environment-related
technologies on ecological footprints over 1992–2016 period
and found that institutional quality posed negative influences
on environmental deterioration. Their results also proved the
validation of EKC in BRICS economies (Hussain & Dogan,
2021). In addition, Khan etal. (2020a) investigated what role
governance played in carbon dioxide emission mitigation in
BRICS nations over 1996 to 2017 period. Authors reported
that better quality governance could assist in the CO2 emis-
sion mitigation, thereby reducing the environmental deterio-
ration in these economies (Baloch and Wang, 2019). There-
fore, the article has developed the following hypothesis:
H4: Institutional quality has a significant impact on GHG
emission in developing countries.
Literature gap
Review of the existing empirical literature indicated that
many earlier studies examined the effect of technology inno-
vations, trade openness, energy efficiency, and institutional
quality on environmental quality regarding individual as
well as panels of different countries. Most of these studies
had a herding behavior in measuring environmental quality
in terms of CO2 emissions. Limited to our knowledge, only
Lee etal. (2021) and Akdag and Yıldırım (2020) measured
the effect of institutional quality and energy efficiency on
GHG emission, respectively, but their studies include Euro-
pean and BRI countries. Beside these two studies, none of
the preceding studies considered the effect of technological
innovations, trade openness, energy efficiency, and institu-
tional quality on GHG emission especially in the context
of Asian economies. Secondly, none of the studies ana-
lyzed the impact of aforementioned variables together in a
model. Therefore, this study intends to fill in this research
gap by examining the impact of technological innovations,
trade openness, energy efficiency, and institutional quality
together on GHG emission in ten Asian economies, thereby
contributing to the Asian economies’ literature.
Econometric methodology anddata sources
Model specification
This study examines the environmental sustainability in ten
Asian countries, namely, India, Indonesia, Malaysia, China,
Philippines, Pakistan, Singapore, Thailand, Sri-Lanka, and
Vietnam over the period 1995–2018 by analyzing the impact
of technological innovations, trade openness, energy effi-
ciency, and institutional quality on GHG emission. The basic
aim in the selection of the countries is that the research-
ers want to investigate the five most emerging developing
countries such as China, Malaysia, Singapore, Indonesia,
and Vietnam and five less emerging developing countries
such as Pakistan, Sri Lanka, India, Thailand, and the Philip-
pines. The general form of the model is presented in Eq.(1).
where GHG is greenhouse gas emissions, EEF is the energy
efficiency, TIN is the technology innovations, TOP is the
trade openness, and INSQ is the institutional quality.
The econometric form of the model is presented in
Eq.(2).
where αo shows the intercept and β1, β2, β3, and β4 denote
the estimates for GHG emission from EEF, TIN, TOP, and
INSQ, respectively. The detailed description of the variables
and data sources are given in the Table1.
(1)
GHG = f(EEF,TIN,TOP,INSQ)
(2)
GHGit =𝛼o+𝛽1EEFit +𝛽2TINit +𝛽3TOPit +𝛽4INSQit +𝜖it
Table 1 Description of the variables and data sources
Variables Acronym Measurement Data source
Greenhouse gas
emission (depend-
ent variable)
GHG Kt of CO2 equivalent World
develop-
ment
indicators
(WDI)
Energy efficiency EEF
Technology innova-
tions
TIN
Trade openness TOP Imports + exports/
GDP
World
develop-
ment
indicators
(WDI)
Institutional quality INSQ
Environmental Science and Pollution Research
1 3
Data, population, andsampling
The current article has the purpose of investigating develop-
ing countries. Thus, the total population of the article is all
the developing countries. The researchers have selected the
ten developing countries (five most emerging and five less
emerging), that is, the selected sample of the study. Thus, the
data were collected from the ten selected countries using a
secondary source like WDI from 1995 to 2018.
Econometric methodology
This study considers advanced and sophisticated economet-
ric techniques when selecting its methodology for empirical
analysis. The procedure of analysis is carried out through six
basic steps as follows:
a. First, Pesarn’ (2004) CSD (cross-sectional dependence)
test is applied to estimate the effects of common shock.
b. Second, the heterogeneity test proposed by Pesaran and
Yamagata (2008) is used to examine the homogeneity/
heterogeneity of slope parameters in data.
c. Third, the stationarity of the selected variables is esti-
mated through the stationarity/unit root tests proposed
by Pesaran (2007) and Bai and Carrion-I-Silvestre
(2009).
d. Fourth, Westerlund and Edgerton (2008) and Banerjee
andCarrion‐i‐Silvestre (2017) panel cointegration tests
are applied to estimate the long-run cointegration among
the variables.
e. Fifth, the short-run and the long-run relationship are
estimated through CS-ARDL (cross-sectionally aug-
mented ARDL) developed by Chudik and Pesaran
(2015).
f. Last, the findings are reconfirmed with the help of the
augmented mean group (AMG) and common correlated
effect mean group (CCEMG). The employed techniques
are discussed in detail below.
Cross‑sectional dependence test
We used the cross-sectional dependence (CSD) test to see
if CSD is present in the data. The CSD examination is
the first step towards formally beginning the panel data
study (Pesaran, 2015). A number of factors including
interdependency of residuals, economic interdependence,
unexpected common stocks volatility, a surge in oil prices,
shocks in demand, and globalization, as well as unob-
served and hidden factors, contribute to the CSD (Shao
etal., 2021). Furthermore, finding the CSD in panel data is
crucial since the Westerlund cointegration and CIPS meth-
ods imply heterogeneity and dependency across distinct
sections. Thus, in order to give the most efficient findings,
the current study used the Pesaran (2007)’s CSD test. Dur-
ing the estimation of the correlation factors, the values of
the means are removed in this test. The null hypothesis
assumes no CSD, opposite to the alternative hypothesis
which states that the CSD is present in data (Ahmad etal.,
2020). The CSD test is given as:
𝝆
2
ij
shows the coefficient of residual pairwise correlation
of the least square residuals. In this case, null hypothesis
cannot be rejected if the panel data does not show any cross-
sectional dependency.
Slope heterogeneity test
Pesaran and Yamagata (2008) developed slope heterogene-
ity test originally attributed to Swamy (1970)).1 This test
is applied in the study to reveal the slope heterogeneity
or homogeneity between the cross-sections under study.
Other homogeneity measures, like the seemingly unrelated
regression equation (SURE) technique, are less preferable
to this test due to the fact that it does not allow for the CSD
(Atasoy, 2017). A homogeneous slope is assumed as the null
hypothesis, while a heterogeneous slope is assumed as the
alternative hypothesis in this test (Shao etal., 2021). The
model of the test is given below:
where
∼
S
= Swamy test statistic and k = number of explana-
tory variables.
∼
ΔSH
denotes the delta tilde,
∼
ΔASH
denotes the adjusted
delta tilde assuming the homogenous slope coefficients as
null hypothesis and heterogeneous slope coefficients as alter-
native hypothesis.
(3)
CD
=
√
2T
N(N−1)
(∑
N−1
i=1
∑
N
j=i+1𝜌 ij
)
∼N(0,1)i,
j
(4)
CD =1, 2, 3, 4 ………10 ………N
(5)
M
=√2T
N(N−1)(
∑
N−1
i=1
∑
N
j=i+1𝜌 ij)(T−k)𝜌
2
ij −E(T−k)𝜌
2
ij
Var (T−k)𝜌 2
ij
(6)
∼
Δ
SH=(N)
1
2(2K)−1∕2
(1
N
S−k
)
(7)
∼
Δ
ASH=(N)
1
2
2k(T−k−1)
T+1
−
1
2
1
N
∼
S−k
1 See Swamy (1970) and Pesaran and Yamagata (2008) for more
details.
Environmental Science and Pollution Research
1 3
Panel unit root tests
After CSD and slope heterogeneity tests, it is necessary
to test the integration order among the variables selected
for the study. In this context, first-generation unit root tests
may give spurious findings if the CSD exists in the data
(Dogan & Seker, 2016). To prevent this bias in the find-
ings, Z. Khanet al. (2020a) proposed employing both para-
metric and non-parametric tests. Therefore, this study used
the cross-sectionally augmented IPS (CIPS) tests proposed
by Pesaran (2007). CIPS has the capability to deal with
the CSD and slope heterogeneity and therefore provides
more reliable and accurate results. The CIPS test equation
is specified as:
where
W
shows the average cross-section and is represented
as:
The CIPS test statistics is stated as:
Moreover, second-generation test introduced by Bai and
Carrion-I-Silvestre (2009) is also used in the study. Many
breaks at structure in heterogeneous panels can be handled
by this panel unit root test. Under varying magnitudes of
shift, breaks are permissible at slope, level, or both at dif-
ferent time periods. It is important to compute the structural
breaks as the time spans the era of the global and Asian
economic crisis. Common factors are used to capture the
CSD as described by Bai and Ng (2004). These common
factors can either be stationary or non-stationary as well as
a combination of both. A modified Sargan-Bhargava (MSB)
test for each series is pooled by this technique after includ-
ing several breaks at structure for every series and common
elements. Three pooling statistics result in three distinct test
statistics: Z, individual statistics standardization and P and
Pm combining their p values. Monte Carlo simulations con-
firm that these tests perform well in infinite samples (Nas-
reen etal., 2020).
Cointegration tests
It is necessary to confirm whether cointegration exists among
the selected variables before estimation of long-run param-
eters. Thus, in order to deal with the problems of the CSD and
slope heterogeneity in the data, this study applies the panel
cointegration techniques proposed by Westerlund and Edg-
erton (2008) and Banerjee and Carrion-i-Silvestre (2017).
These estimations have the advantage of incorporating the
(8)
Δ
Wi,t=∅
i+∅
iZi,t−1+∅
iZt−1+
∑p
l=0
∅ilΔWt−1+
∑p
l=0
∅ilΔWi,t−1+𝜇
it
(9)
W
i,t
=∅
1
EEFi,t
+∅
2
TINi,t
+∅
3
TOPi,t
+∅
4
INSQ
i,
t
(10)
CIPS
=N−1
∑n
i=1
CADF
i
detection of cointegration with breaks at structure. Westerlund
and Edgerton (2008) technique handles the problems of CSD,
heterogeneous slopes, serially correlated disturbance terms,
and structural at each cross-section in contrast to the first-and
second-generation tests. The LM unit root technique of Ahn
(1993), Schmidt and Phillips (1992), and Amsler and Lee
(1995) provide the basis for Westerlund and Edgerton (2008)
test. The test model is presented below with the null hypothesis
of no cointegration (with breaks) and the alternative hypoth-
esis of cointegration (with breaks):
where i = 1 to N and t = 1 to T. xit is specified as a random
walk, and it contains explanatory variables. Dit represents
a scalar break dummy variable such that Dit equals 1 if t
is greater than Ti and zero otherwise. Intercept specific for
cross unit and slope coefficient earlier to break are repre-
sented by αi and βi, respectively, while the changes in these
parameters after the break are denoted by δi and γi. The dis-
turbance zit is assumed to allow CSD by using unobservable
common factors Ft.
where
∅
i(L)=1−
∑p
i
j=1
∅ijL
j
is a lag operator’s scalar poly-
nomial. L, Ft is a re-dimensional vector of unobservable
common factors (Fit) with j equal to 1—r, and λi is the factor
loading parameters vector. The relationship in Eq. (i) is co-
integrated if ϕi is less than zero and it is biased if ϕi equals
zero.
Two LM-based statistics are defined by Westerlund and
Edgerton (2008):
where
∅𝐢
is the estimate of ϕi ( least square estimate) and
𝝈i
is its estimated standard error,
wi
represents the long-run
variance of Δνit, and SE
(
∅𝐢
)
denotes the standard error of
∅𝐢
(Damette & Seghir, 2013).
The panel cointegration test developed by Banerjee and
Carrion-i-Silvestre (2017) is also applied in this study. It
implies that CSD is linked to common variables as meas-
ured by the averages of each cross-sectional variable. There
is flexibility in using this test of cointegration as it permits
panel data structural breaks (Le & Ozturk, 2020).
(11)
yit
=∝
i
+𝜇
i
t+𝛿
i
D
it
+x�
it
𝛽
i
+
(
D
it
x
it)�
𝛾
i
+z
it
(12)
xit =xit−1+wit
(13)
zit
=λ
�
i
F
t
+v
it
(14)
Fit =𝜌jFjt−1+ujt
(15)
∅it(L)Δvit =∅
ivit−1+e
it
(16)
LM
∅(i)=T
∅iwi
𝜎 iand LMT(i)=
∅i
SE
∅
i
Environmental Science and Pollution Research
1 3
Short‑run andlong‑run estimation (CS‑ARDL)
After performing these preliminary estimations,
we analyzed the short-run and the long-run relation
between the dependent and independent variables. For
the long-run analysis of the panel data, economists
have proposed multiple techniques. Many of the ear-
lier studies have a herding behavior in applying first-
generation techniques (e.g. DOLS, FMOLS, ARDL)
which do not produce reliable findings if slope hetero-
geneity and CSD are present in the data. Therefore, we
applied the CS-ARDL estimation proposed by Chudik
and Pesaran (2015) to deal the slope heterogeneity and
CSD present in data. CS-ARDL technique can easily
be implemented in empirical terms and is helpful to
remove bias in the data. The CS-ARDL approach in its
general form is given below.
CSA stands for cross-sectional averages and is further
represented by
CSA
t=
(
ΔYt,
EXVs,t
)�
variables; i.e., explan-
atory variables are shown by EXV's.
CCEMG (common correlated effects mean group)
The CCEMG (common correlated effects mean group) and
AMG (augmented mean group) are two contemporary panel
data estimation approaches robust to CSD and slope hetero-
geneity. Pesaran (2007) developed CCEMG, and it is further
strengthened by Kapetanios etal. (2011) which is robust to
breaks at structure and non-stationary common factors that
are unobserved. CCE estimator is given as follows:
where βi is the slope of the regressors
xit
, α1i denotes the
fixed effects that captures the heterogeneity among groups
that is time invariant, ft is the common factor (unobserved)
with heterogeneous factor loadings (ϕi), and εit is the dis-
turbance term. Above equation is augmented with depend-
ent and explanatory variables cross-sectional averages as
follows:
In the case of slope heterogeneity, the whole panel inference
is made by estimator of mean group. For the CCE, the mean
group estimator is calculated as follows:
𝜷i
is the coefficient estimates.
(17)
Δ
Yit =𝜑i+
∑p
l=1
𝜑itΔYi,t−1+
∑p
l=0
𝜑
�
il
EXVs,i,t+
∑1
l=0
𝜑
�
il
CSAi,t−1+𝜀
it
(18)
yit =a1i+𝛽ixit +𝜑ift+𝜀it
(19)
yit =a1i+𝛽ixit +𝛿iyit +𝜃ixit +𝜑ift+𝜀it
(20)
CCEMG
=N−1
∑N
i=1
𝛽
i
AMG (augmented mean group)
The second approach used is the AMG (augmented mean
group) estimation proposed by Bond and Eberhardt (2013)
and Eberhardt and Teal (2010). Like CCEMG, AMG is also
robust to heterogeneous slope and CSD. The difference exists
between CCEMG and AMG estimations only in the computa-
tion of the unobservable common factors ft in (p). The cross-
sectional combinations means the observed common effects
and the dependent and independent variables are used in
CCEMG estimation. After this, every coefficient is estimated
by ordinary least squares. AMG estimation follows a two-step
procedure for the estimation of the unknown common dynamic
effects and permits CSD by adding the parameter of common
dynamic effect. In first step, the equation is augmented with
dummy variables for time and is estimated by the first differ-
ence ordinary least square method.
Δ shows the difference operator, and τ shows the time
dummy coefficient known as common dynamic process. In
the 2nd step, it augments the regression model (group spe-
cific) with an explicit variable or coefficient on each group
member. Estimator of AMG is subtracted from the explained
variable to impose the implementation of the unit coefficient.
Like CCEMG estimator, it also averages the model parameters
across the panel. The intercept is added in each regression that
captures the fixed effects that are time invariant. The AMG
mean group estimator is given as follows.
where,
∼
𝜷i
is the estimates of coefficients in the following
equation:
Empirical results
Before evaluating the stationarity of the variables, the CSD
is checked in the panel. The Pesaran (2007) CSD technique
is used for this estimation and Table2 shows the results.
The estimations show that CSD is present in the data as
null hypothesis cannot be accepted at 1% significance level.
After evaluating the CSD, we estimated the homogeneity
of the slope parameters by applying Pesaran and Yamagata
(2008) slope homogeneity test based on delta
∼
(Δ)
and
adjusted delta
(∼
Δadj
)
. The outcomes of the test are given in
Table3.
(21)
Δ
yit =a1i+𝛽iΔxit +𝜑ift+
∑T
t=2
𝜏tDUMMYt+𝜀
it
(22)
AMG
=N−1
∑
N
i=1
∼
𝛽
i
(23)
Δ
yit =a1i+𝛽iΔxit +𝜑ift+
∑T
t=2
𝜏tDUMMYt+𝜀
it
Environmental Science and Pollution Research
1 3
The results reveal that slopes are heterogeneous as the
null hypothesis is clearly abandoned at 1% level of signifi-
cance showing that GHG emissions, EEF, TOP, TIN, and
INSQ vary among selected Asian countries.
Since CSD is present and slopes are heterogeneous, the
next step is to test the unit root/stationarity of every series.
For this purpose, Bai and Carrion-I-Silvestre (2009) tests
for unit root/stationarity are applied and their results are
given in the following Table4.
Bai and Carrion-i-Silvestre (2009): for Z and Pm statis-
tics, the critical values 2.326, 1.645, and 1.282 are for 1,
5, and 10% significance levels, respectively, whereas for
P, critical values are 56.06, 48.60, and 44.90, separately.
It is indicated from the results of CIPS and M-CIPS that
the null hypothesis cannot be accepted, and it is concluded
that all the series are stationary at level. However, the find-
ings of Bai and Carrion-I-Silvestre (2009) indicate that
GHG, EEF, TOP, TIN, and INSQ represent the unit root at
the level. However, there is no unit root problem (station-
ary) at the first difference in these variables.
After stationary tests, the cointegration tests of West-
erlund and Edgerton (2008) and Banerjee and Carrion-i-
Silvestre (2017) allowing structural break are carried out.
The estimates of Westerlund and Edgerton (2008) are given
in Table5.
The test results confirm the cointegration relationship
among GHG, TOP, TIN, EEF, and INSQ without break, at
mean and at regime shift.
In addition, we carried out Banerjee and Carrion-i-Sil-
vestre (2017) cointegration estimation and long-run coin-
tegration and a steady relationship with constant and trend
are confirmed by the results for the entire sample as given
in Table6.
Table 2 CSD test results
*** , **, and * show significance at 1, 5, and 10% levels, respectively,
whereas P values are given in parantheses
Variable Test statistics (p values)
GHG 19.102*** (0.000)
EEF 22.001*** (0.000)
TIN 18.101*** (0.000)
TOP 21.100*** (0.000)
INSQ 17.654*** (0.000)
Table 3 Slope heterogeneity test results
*** , **, and * show significance at 1, 5, and 10% level, whereas par-
antheses contain P value
Explained variable: GHG
Test statistics Test value and P value
Delta tilde 46.012*** (0.000)
Adjusted Delta tilde 58.075*** (0.000)
Table 4 Unit root results: with
and without structural break
(Pesaran (2007)
* , **, and *** show the significance at 10, 5, and 1% levels, respectively
Level I(0) 1st Difference I(1)
Variables CIPS M-CIPS CIPS M-CIPS
GHG − 3.010*** − 4.123** - -
EEF − 5.020*** − 6.010** - -
TIN − 3.003*** − 4.101** - -
TOP − 4.110*** − 5.321** - -
INSQ − 5.050*** − 6.030** - -
Bai and Carrion-i-Silvestre (2009)
Z PmP Z PmP
GHG 0.312 0.495 20.101 − 3.030*** 4.002*** 45.023***
EEF 0.430 0.525 17.010 − 5.011*** 6.100*** 25.063***
TIN 0.391 0.414 23.201 − 4.202*** 5.030*** 57.056***
TOP 0.591 0.620 19.006 − 3.003*** 4.251*** 44.084***
INSQ 0.333 0.405 16.301 − 5.125*** 6.006*** 36.052***
Table 5 Westerlund and Edgerton (2008) panel cointegration results
10%, 5%, and 1% significance levels are denoted by *, **, and ***,
respectively, and parentheses contain P value
Test No break Mean shift Regime shift
Explained variable: GHG
Zφ(N) − 3.130*** − 3.010*** − 4.121***
Pvalue 0.000 0.000 0.000
Zτ(N) − 4.141*** − 4.000*** − 5.050***
Pvalue 0.000 0.000 0.000
Environmental Science and Pollution Research
1 3
Country-based analysis reported in the above table also
verifies co integration and steady connection for all countries
with both constant and trend. On the basis of the critical
values, the results given above are significant at 5% level of
significance.
After completing preliminary analysis, now we proceed
to the long-run and short-run estimation of the relationship
of the panel variables. As CSD and slope heterogeneity are
present in our data, the cross-sectional autodistributive
lag model (CS-ARDL) is applied to investigate the output
coefficients. The test results are reported in Table7.
The results reveal a negative relationship between
energy efficiency and GHG emissions. A one-unit rise in
energy efficiency reduces GHG emission by 0.28 units in
the long term and 0.086 units in the short term in Asian
countries. Thus, energy efficiency appears to be a potential
technique to reduce GHG emissions in the panel coun-
tries, enhancing environmental quality in turn. Energy effi-
ciency is helpful to reduce emissions of GHG by sustain-
ing energy in the transportation and construction sectors.
In recent researches, a negative relation between energy
efficiency and GHG emissions was also reported by Akdag
and Yıldırım (2020) for China and Akram, Akram etal.
(2020a) for developing and BRICS economies. However,
a positive relationship was found by Irfan etal. (2021) for
South Asian economies.
Next, the environmental impact of technology innova-
tions is significant and negative. The findings reveal that
a one-unit increase in technology innovations decreases
GHG emissions by 0.24 units in the long run and 0.04
units in the short run. It indicates that technology innova-
tions are significantly and positively related to environ-
ment quality in Asian countries. One possible explana-
tion is that technology innovations increase a country’s
potential to replace harmful resources with ecologically
benign ones. To deal with environmental concerns, a
country can, for example, change traditional resources of
energy production to renewable energy resources. Con-
tinuous innovation, research and development (R&D), new
technological development, and other forms of innovation
have a direct effect on energy efficiency and industrial per-
formance. As a result, innovation can help to reduce GHG
emissions, and promoting technology innovations can help
these countries move toward cleaner economies.
The findings divulge a significantly positive influence
of trade openness on GHG emissions both in the short and
long run. A one-unit increase in trade liberalization increases
GHG emission by 0.195 in the long run and 0.212 units
in the short run. This result supports the pollution haven
hypothesis, suggesting that increased liberalization in trade
opens the door to environmental degradation because with
an increase in level of income, demand for clean environ-
ment increases and dirty corporations of developed econo-
mies emitting high level of GHG and other environmental
pollutants look for areas having lesser strict environmen-
tal legislation. As the majority of the Asian developing
countries lack comprehensive environmental rules, (e.g.,
China, India, and Indonesia), companies of the developed
Table 6 Banerjee and Carrion-i-Silvestre (2017) results
With constant, CV (critical value) at 10%* and 5%** is − 2.18
and − 2.32, whereas with trend CV is − 2.82. and − 2.92
Countries No deterministic
specification
With constant With trend
Explained variable: GHG
Full sample − 4.032*** − 4.010** − 5.110**
China − 3.011*** − 3.001** − 4.041**
India − 6.010*** − 5.100** − 7.010**
Indonesia − 6.123*** − 5.321** − 7.107**
Malaysia − 5.025*** − 4.404** − 6.006**
Pakistan − 5.753*** − 4.321** − 6.420**
Philippines − 3.951*** − 3.151** − 4.114**
Singapore − 7.100*** − 6.060** − 8.001**
Sri-Lanka − 4.150*** − 4.004** − 5.011**
Thailand − 4.424*** − 5.020** − 6.112**
Vietnam − 3.110*** − 3.002** − 4.020**
Table 7 CS-ARDL analysis:
short run and long run results
* , **, and *** represent significance at 10%, 5%, and 1% levels, respectively
Explained variable: GHG emission
Long run Short run
Variables Coeff t-stat P-value Coeff t-stat P -value
EEF − 0.286*** − 3.456 0.000 − 0.086*** − 4.100 0.000
TIN − 0.246* − 1.673 0.094 − 0.040*** − 5.125 0.000
TOP 0.195*** 3.002 0.000 0.212*** 3.100 0.000
INSQ 0.300** 2.211 0.041 0.071*** 6.142 0.000
ECT(-1) − 0.312*** − 4.040 0.000
CSD-Statistics - - - 0.055 0.720
Environmental Science and Pollution Research
1 3
economies (having higher environmental legislations) shift
their factories and plants to these countries with lax envi-
ronmental rules and regulations. Thus, with trade openness,
these host economies with lax environmental laws and regu-
lations become dirtier (Ertugrul etal., 2016). Moreover, it is
true that underdeveloped countries are more focused on con-
ventional sources of energy, which result in higher emissions
resulting from more industrialization and human actions as
a result of trade liberalization.
For each unit increase in institutional quality, GHG emis-
sions rise by 0.300 units in the long run and by 0.07 units
in the short run. This increase indicates that in the selected
countries, higher institutional quality may provide more
political freedom and civil liberties to general public. The
findings also indicate that the political situation in these
countries is less concerned with issues of general public like
pollution caused by GHG emissions. While some countries’
political–institutional systems may have taken steps to prior-
itize environmental quality, changing bureaucratic mindsets
to prioritize environmental issues may still take time. The
results of institutional quality in these economies indicate
that economic progress and industrialization appear to be
top priorities; hence, institutional quality improvement is
becoming a reason of fast industrial progress and contribut-
ing to increased pollution (Azam etal., 2021). Moreover, the
error correction term (ECT) meets all three conditions; i.e.,
it is negative, significant, and less than one in magnitude.
Its coefficient is 0.312, which signifies the 31% adjustment
speed towards long-run equilibrium. For the robustness of
the analysis, econometric approaches of AMG and CCEMG
are applied finally, and their results are given in the Table8.
The current study has run a robust test to check and
support the study results extracted from the CS-ARDL
model. The robust results of AMG and CCEMG support
our short- and long-run findings. Energy efficiency causes
decrease in GHG emission by 0.043 units AMG and 0.237
units CCEMG. Similarly, 0.075 units decrease for AMG and
0.131 units decrease for CCEMG in GHG are caused by
technological innovations. Trade openness causes a rise in
GHG emissions of 0.171 units for AMG and 0.297 units
for CCEMG. And an increase of 0.222 units for AMG and
0.166 units for CCEMG in GHG emission is caused by
institutional quality. The significant P value of Wald Test
evidenced that the model is highly significant.
Discussions
The current article results exposed that energy efficiency
has a negative impact on GHG emission that shows the
energy efficiency reduce GHG emissions. These findings
support the arguments of the previous studiesthat energy
efficiency is critical for decreasing emissions and high-
light the significance of energy efficiency improvements
in reducing GHG emissions in developing economies. In
addition, the results of the present article also exposed the
negative linkage among technology innovation and GHG
emission that show selected developing countries adopted
high-technology innovation that reduces the GHG emission.
Similar results were reported by R. L. Ibrahim and Ajide
(2021), Long etal. (2018), Omri and Hadj (2020), and Hod-
son etal. (2018), but opposite results were found by Ganda
(2019), Yu and Du (2019), and Erdoğan etal. (2020). The
findings also revealed that trade openness increases GHG
emissions, which is the reason of the positive association
among GHG emissions and trade openness. These outcomes
are in line with Dauda etal. (2021); Ali etal. (2020); and
Zameer etal. (2020), who also observed that trade openness
affected emissions positively. The adverse effect of trade
openness on environmental quality is reported by Tachie
etal. (2020) in 18 European Union countries and Amin
etal. (2020) in Asian economies.
The results of the current article also identified a sig-
nificant and positive link between institutional quality and
GHG emissions. Similar results are reported by Godil etal.
(2020), Azam etal. (2021), and Chaudhry etal. (2021) in
the literature.
Conclusion andpolicy recommendations
Thus, based on the study results, the current article con-
cluded that the Asian countries do not have quality institu-
tions that do not play a significant role in reducing GHG
emission, which is the reason for the positive association
Table 8 AMG and CCEMG
results
* , **, and *** represent significance at 10%, 5%, and 1% levels, respectively
Dependent vari-
ables GHG
(AMG) (CCEMC)
Coeff t-stat pvalues Coeff t-stat p values
EEF − 0.043*** − 4.101 0.000 − 0.237*** − 6.003 0.000
TIN − 0.075*** − 3.031 0.000 − 0.131*** − 3.100 0.000
TOP 0.171*** 4.004 0.000 0.297*** 5.654 0.000
INSQ 0.222*** 3.123 0.000 0.166*** 4.001 0.000
Wald test - 44.65 0.000 - 18.088 0.000
Environmental Science and Pollution Research
1 3
among institutional quality and GHG emission. In addi-
tion, the selected developing countries are more focused on
energy efficiency in reducing GHG emission, which is the
reason of energy efficiency has a negative impact on GHG
emission. Results of the study provide evidence that trade
openness has a favorable effect on GHG emissions both in
the short and in the long run. Finally, the selected developing
countries are implementing effective technology innovation,
which is the reason of technology innovation reduce GHG
emission and current study findings show a negative linkage
among technology innovation and GHG emission in devel-
oping countries.
On the basis of the results, some policies are recom-
mended for the governments of the selected countries. First,
it is critical to strengthen institutions and empower them to
function effectively in these countries. Effective institutional
operations, especially the private institutions’ operations,
would result in the successful implementation of rules and
regulations, which would aid in the battle against corrup-
tion and, if carefully monitored, would result in a reduction
in GHG emissions in the countries. Second, governments
in Asian nations should keep improving cooperation with
advanced countries that are at the forefront of technology
innovations and should allocate more resources in research
and development activities to generate novel innovations.
This will aid Asian countries in mastering clean-environ-
ment technology, as an excessive level of emissions in devel-
oping countries may have a global detrimental impact on
environmental quality.
Third, countries should develop efficient energy effi-
ciency policies and work together to improve energy effi-
ciency to meet the Paris Agreement’s global climate goals
and sustainable development goals. They should collaborate
on projects to help spread knowledge and promote energy-
efficient technologies. Finally, governments should encour-
age trade-related environmental regulations and use of envi-
ronmentally friendly and clean technologies during trade
goods production. Furthermore, increasing the participation
of tertiary industry in FDI is a viable strategy to aid in the
reduction of pollution as international trade liberalizes. In
addition, the current article also suggested to the regulators
that they should gain regional co-operation while developing
the policies related to the multi-lateral trade.
Limitations andfuture directions
The present article has some limitations that provide the
direction for upcoming researchers. The current study
has taken only four predictors such as institutional qual-
ity, trade openness, energy efficiency, and technology
innovation and ignored many factors and recommended
that upcoming studies should add these factors in the
analysis. In addition, the current research has taken ten
developing countries in the analysis and ignored many
emerging developing countries and developed countries
that narrow down the study scope and suggested that
future studies should add these countries in the studies.
Finally, the current article has also taken limited years
under investigation, such as the data were gathered from
1995 to 2018 that also narrowed down the study scope
and recommended that future studies should add more
years in the analysis.
Author contribution Zheng Wenlong: writing—original draft. Nguyen
Hoang Tien: methodology supervision. Amena Sibghatullah: con-
ceptualization, writing—review and editing. Daru Asih: software.
Mochamad Soelton: data curation. Yanto Ramli: visualization and
formatting.
Funding This research is funded by 2020 national social science fund
major project “Research on the spatial effects of cross regional major
infrastructure in China” (approval No.: 20 & zd099), participated in
the sub-project “integration of cross regional major infrastructure and
Urban Agglomeration.”
Data availability The data that support the findings of this study are
attached.
Declarations
Ethics approval and consent to participate We declare that we have no
human participants, human data, or human tissues.
Consent for publication Not Applicable.
Competing interests The authors declare no competing interests.
References
Ahmad M, Jiang P, Majeed A, Umar M, Khan Z, Muhammad S (2020)
The dynamic impact of natural resources, technological innova-
tions and economic growth on ecological footprint: an advanced
panel data estimation. Resour Policy 69:101817
Ahn SK (1993) Some tests for unit roots in autoregressive-inte-
grated-moving average models with deterministic trends.
Biometrika 80(4):855–868
Akdag S, Yıldırım H (2020) Toward a sustainable mitigation
approach of energy efficiency to greenhouse gas emissions in
the European countries. Heliyon 6(3):e03396
Akram R, Chen F, Khalid F, Ye Z, Majeed MT (2020a) Heteroge-
neous effects of energy efficiency and renewable energy on
carbon emissions: evidence from developing countries. J Clean
Prod 247:119122
Akram R, Majeed MT, Fareed Z, Khalid F, Ye C (2020b) Asym-
metric effects of energy efficiency and renewable energy on
carbon emissions of BRICS economies: evidence from non-
linear panel autoregressive distributed lag model. Environ Sci
Pollut Research, 27(15).
Al-mulali U, Sheau-Ting L (2014) Econometric analysis of trade,
exports, imports, energy consumption and CO2 emission in six
regions. Renew Sustain Energy Rev 33:484–498
Environmental Science and Pollution Research
1 3
Ali HS, Zeqiraj V, Lin WL, Law SH, Yusop Z, Bare UAA, Chin L
(2019) Does quality institutions promote environmental qual-
ity? Environ Sci Pollut Res 26(11):10446–10456
Ali S, Yusop Z, Kaliappan SR, Chin L (2020) Dynamic common cor-
related effects of trade openness, FDI, and institutional perfor-
mance on environmental quality: evidence from OIC countries.
Environ Sci Pollut Res 1–12.
Alola AA (2019) The trilemma of trade, monetary and immigration
policies in the United States: accounting for environmental
sustainability. Sci Total Environ 658:260–267
Amin A, Aziz B, Liu X-H (2020) The relationship between urbaniza-
tion, technology innovation, trade openness, and CO 2 emis-
sions: evidence from a panel of Asian countries. Environ Sci
Pollut Res 27(28):35349–35363
Amsler C, Lee J (1995) An LM test for a unit root in the presence of
a structural change. Economet Theor 11(2):359–368
Ansari MA, Haider S, Khan N (2020) Does trade openness affects
global carbon dioxide emissions: evidence from the top CO2
emitters. Manag Environ Q: Int J.
Ansari MA, Khan NA, Ganaie AA (2019) Does foreign direct invest-
ment impede environmental quality in Asian countries? A
panel data analysis. OPEC Energy Rev 43(2):109–135
Atasoy BS (2017) Testing the environmental Kuznets curve hypoth-
esis across the US: Evidence from panel mean group estima-
tors. Renew Sustain Energy Rev 77:731–747
Atici C (2012) Carbon emissions, trade liberalization, and the Japan–
ASEAN interaction: A group-wise examination. J Jpn Int Econ
26(1):167–178
Azam M, Liu L, Ahmad N (2021) Impact of institutional quality on
environment and energy consumption: evidence from develop-
ing world. Environ Dev Sustain 23(2):1646–1667
Bai J, Carrion-I-Silvestre JL (2009) Structural changes, common
stochastic trends, and unit roots in panel data. Rev Econ Stud
76(2):471–501
Bai J, Ng S (2004) A PANIC attack on unit roots and cointegration.
Econometrica 72(4):1127–1177
Baloch MA, Wang B (2019) Analyzing the role of governance in
CO2 emissions mitigation: the BRICS experience. Struct
Chang Econ Dyn 51:119–125
Baloch ZA, Tan Q, Kamran HW, Nawaz MA, Albashar G, Hameed
J (2021) A multi-perspective assessment approach of renew-
able energy production: policy perspective analysis. Environ
Dev Sustain 1-29https:// doi. org/ 10. 1007/ s10668- 021- 01524-8
Balsalobre-Lorente D, Shahbaz M, Roubaud D, Farhani S (2018)
How economic growth, renewable electricity and natu-
ral resources contribute to CO2 emissions? Energy Policy
113:356–367
Banerjee A, Carrion-i-Silvestre JL (2017) Testing for panel cointegra-
tion using common correlated effects estimators. J Time Ser Anal
38(4):610–636
Bond S, Eberhardt M (2013) Accounting for unobserved heterogeneity
in panel time series models. University of Oxford, 1–11.
Brookes L (1990) The greenhouse effect: the fallacies in the energy
efficiency solution. Energy Policy 18(2):199–201
Chaturvedi V, Shukla PR (2014) Role of energy efficiency in climate
change mitigation policy for India: assessment of co-benefits and
opportunities within an integrated assessment modeling frame-
work. Clim Change 123(3):597–609
Chaudhry IS, Ali S, Bhatti SH, Anser MK, Khan AI, Nazar R (2021)
Dynamic common correlated effects of technological innova-
tions and institutional performance on environmental quality:
Evidence from East-Asia and Pacific countries. Environ Sci
Policy 124:313–323
Cheng S, Meng L, Xing L (2021) Energy technological innovation and
carbon emissions mitigation: evidence from China. Kybernetes.
Chien F, Sadiq M, Nawaz MA, Hussain MS, Tran TD, Le Thanh T
(2021a) A step toward reducing air pollution in top Asian econo-
mies: The role of green energy, eco-innovation, and environmen-
tal taxes. J Environ Manage. https:// doi. org/ 10. 1016/j. jenvm an.
2021. 113420
Chien F, Hsu CC, Ozturk I, Sharif A, Sadiq M (2021b) The role of
renewable energy and urbanization towards greenhouse gas
emission in top Asian countries: Evidence from advance panel
estimations. Renewable Energy. https:// doi. org/ 10. 1016/j. renene.
2021. 12. 118
Chien F, Zhang Y, Sadiq M, Hsu CC (2021c) Financing for energy effi-
ciency solutions to mitigate opportunity cost of coal consump-
tion: An empirical analysis of Chinese industries. Environ Sci
Pollut Res. https:// doi. org/ 10. 1007/ s11356- 021- 15701-9
Chien F, Ananzeh M, Mirza F, Bakar A, Vu HM, Ngo TQ (2021d)
The effects of green growth, environmental-related tax, and eco-
innovation towards carbon neutrality target in the US economy. J
Environ Manage. https:// doi. org/ 10. 1016/j. jen vm an. 2021. 113633
Chien F, Sadiq M, Kamran HW, Nawaz MA, Hussain MS, Raza M
(2021e) Co-movement of energy prices and stock market return:
environmental wavelet nexus of COVID-19 pandemic from the
USA, Europe, and China. Environ Sci Pollut Res. https:// doi. org/
10. 1007/ s11356- 021- 12938-2
Chudik A, Pesaran MH (2015) Common correlated effects estimation
of heterogeneous dynamic panel data models with weakly exog-
enous regressors. J Econom 188(2):393–420
Damette O, Seghir M (2013) Energy as a driver of growth in oil export-
ing countries? Energy Econ 37:193–199
Dauda L, Long X, Mensah CN, Salman M, Boamah KB, Ampon-
Wireko S, Dogbe CSK (2021) Innovation, trade openness and
CO2 emissions in selected countries in Africa. J Clean Prod
281:125143
Destek MA, Ulucak R, Dogan E (2018) Analyzing the environmental
Kuznets curve for the EU countries: the role of ecological foot-
print. Environ Sci Pollut Res 25(29):29387–29396
Dogan E, Seker F (2016) The influence of real output, renewable and
non-renewable energy, trade and financial development on car-
bon emissions in the top renewable energy countries. Renew
Sustain Energy Rev 60:1074–1085
Eberhardt M, Teal F (2010) Ghana and Côte d’Ivoire: Changing Places.
International Development Policy| Revue internationale de poli-
tique de développement(1), 33–49.
Emir F, Bekun FV (2019) Energy intensity, carbon emissions, renew-
able energy, and economic growth nexus: new insights from
Romania. Energy Environ 30(3):427–443
Erdoğan S, Yıldırım S, Yıldırım DÇ, Gedikli A (2020) The effects
of innovation on sectoral carbon emissions: evidence from G20
countries. J Environ Manag 267:110637
Ertugrul HM, Cetin M, Seker F, Dogan E (2016) The impact of trade
openness on global carbon dioxide emissions: Evidence from
the top ten emitters among developing countries. Ecol Ind
67:543–555
Ganda F (2019) The impact of innovation and technology investments
on carbon emissions in selected organisation for economic Co-
operation and development countries. J Clean Prod 217:469–483
Godil DI, Sharif A, Agha H, Jermsittiparsert K (2020) The dynamic
nonlinear influence of ICT, financial development, and institu-
tional quality on CO2 emission in Pakistan: new insights from
QARDL approach. Environ Sci Pollut Res 27(19):24190–24200
Goulder LH, Mathai K (2000) Optimal CO2 abatement in the pres-
ence of induced technological change. J Environ Econ Manag
39(1):1–38
Greening LA, Greene DL, Difiglio C (2000) Energy efficiency and
consumption—the rebound effect—a survey. Energy Policy
28(6–7):389–401
Environmental Science and Pollution Research
1 3
Hao W, Rasul F, Bhatti Z, Hassan MS, Ahmed I, Asghar N (2021) A
technological innovation and economic progress enhancement:
an assessment of sustainable economic and environmental man-
agement. Environ Sci Pollut Res 28(22):28585–28597
Hasanbeigi A, Price L, Lin E (2012) Emerging Energy-efficiency and
CO {sub 2} Emission-reduction Technologies for Cement and
Concrete Production: Lawrence Berkeley National Lab.(LBNL),
Berkeley, CA (United States).
Hasanov FJ, Liddle B, Mikayilov JI (2018) The impact of international
trade on CO2 emissions in oil exporting countries: Territory vs
consumption emissions accounting. Energy Econ 74:343–350
Hodson EL, Brown M, Cohen S, Showalter S, Wise M, Wood F, . . .
Cleary K (2018) US energy sector impacts of technology innova-
tion, fuel price, and electric sector CO2 policy: results from the
EMF 32 model intercomparison study. Energy Econ, 73, 352-370
Hossain MS (2011) Panel estimation for CO2 emissions, energy con-
sumption, economic growth, trade openness and urbanization of
newly industrialized countries. Energy Policy 39(11):6991–6999
Ehsanullah S, Tran QH, Sadiq M, Bashir S, Mohsin M, Iram R (2021)
How energy insecurity leads to energy poverty? Do environmen-
tal consideration and climate change concerns matters. Environ
Sci Pollut Res. https:// doi. org/ 10. 1007/ s11356- 021- 14415-2
Hsu CC, Quang-Thanh N, Chien F, Li L, Mohsin M (2021) Evaluat-
ing green innovation and performance of financial development:
mediating concerns of environmental regulation. Environ Sci
Pollut Res. https:// doi. org/ 10. 1007/ s11356- 021- 14499-w
Huang SZ, Sadiq M, Chien F (2021a) The impact of natural resource
rent, financial development, and urbanization on carbon
emission. Environ Sci Pollut Res. https:// doi. org/ 10. 1007/
s11356- 021- 16818-7
Huang SZ, Sadiq M, Chien F (2021b) Dynamic nexus between trans-
portation, urbanization, economic growth and environmental
pollution in ASEAN countries: does environmental regula-
tions matter? Environ Sci Pollut Res. https:// doi. org/ 10. 1007/
s11356- 021- 17533-z
Huang SZ, Chien F, Sadiq M (2021c) A gateway towards a sustainable
environment in emerging countries: the nexus between green
energy and human Capital. Econ Res-Ekon Istraživanja. https://
doi. org/ 10. 1080/ 13316 77X. 2021. 20122 18
Hussain M, Dogan E (2021) The role of institutional quality and envi-
ronment-related technologies in environmental degradation for
BRICS. J Clean Prod 304:127059
Ibrahim MH, Law SH (2016) Institutional Quality and CO2 Emission-
Trade Relations: Evidence from S ub-S aharan A frica. S Afr J
Econ 84(2):323–340
Ibrahim RL, Ajide KB (2021) Disaggregated environmental impacts of
non-renewable energy and trade openness in selected G-20 coun-
tries: the conditioning role of technological innovation. Environ
Sci Pollut Res, 1–15.
Irfan M, Mahapatra B, Ojha RK (2021) Examining the effectiveness
of low-carbon strategies in South Asian countries: the case of
energy efficiency and renewable energy. Environ Dev Sustain
1–17.
Javid M, Khan M (2020) Energy efficiency and underlying carbon
emission trends. Environ Sci Pollut Res 27(3):3224–3236
Kapetanios G, Pesaran MH, Yamagata T (2011) Panels with non-sta-
tionary multifactor error structures. J Econom 160(2):326–348
Khan A, Muhammad F, Chenggang Y, Hussain J, Bano S, Khan MA
(2020a) The impression of technological innovations and natural
resources in energy-growth-environment nexus: a new look into
BRICS economies. Sci Total Environ 727:138265
Khan MTI, Yaseen MR, Ali Q (2017) Dynamic relationship between
financial development, energy consumption, trade and green-
house gas: comparison of upper middle income countries from
Asia, Europe, Africa and America. J Clean Prod 161:567–580
Khan Z, Ali S, Umar M, Kirikkaleli D, Jiao Z (2020b) Consumption-
based carbon emissions and international trade in G7 countries:
the role of environmental innovation and renewable energy. Sci
Total Environ 730:138945
Le HP, Ozturk I (2020) The impacts of globalization, financial develop-
ment, government expenditures, and institutional quality on CO
2 emissions in the presence of environmental Kuznets curve.
Environ Sci Pollut Res 27(18):22680–22697
Lee HS, Arestis P, Chong SC, Yap S, Sia BK (2021) The heterogeneous
effects of urbanisation and institutional quality on greenhouse
gas emissions in Belt and Road Initiative countries. Environ Sci
Pollut Res, 1–19.
Li W, Chien F, Kamran HW, Aldeehani TM, Sadiq M, Nguyen VC,
Taghizadeh-Hesary F (2021) The nexus between COVID-19 fear
and stock market volatility. Econ Res-Ekon Istraživanja. https://
doi. org/ 10. 1080/ 13316 77X. 2021. 19141 25
Liu Z, Tang YM, Chau KY, Chien F, Iqbal W, Sadiq M (2021a) Incor-
porating strategic petroleum reserve and welfare losses: A way
forward for the policy development of crude oil resources in
South Asia. Resour Policy. https:// doi. org/ 10. 1016/j. resou rpol.
2021. 102309
Liu Z, Lan J, Chien F, Sadiq M, Nawaz MA (2021b) Role of tour-
ism development in environmental degradation: A step towards
emission reduction. J Environ Manage. https:// doi. org/ 10. 1016/j.
jenvm an. 2021. 114078
Lin B, Ahmad I (2017) Analysis of energy related carbon dioxide
emission and reduction potential in Pakistan. J Clean Prod
143:278–287
Ling CH, Ahmed K, Muhamad RB, Shahbaz M (2015) Decomposing
the trade-environment nexus for Malaysia: what do the technique,
scale, composition, and comparative advantage effect indicate?
Environ Sci Pollut Res 22(24):20131–20142
Long X, Luo Y, Wu C, Zhang J (2018) The influencing factors of CO
2 emission intensity of Chinese agriculture from 1997 to 2014.
Environ Sci Pollut Res 25(13):13093–13101
Lv Z, Xu T (2019) Trade openness, urbanization and CO2 emissions:
dynamic panel data analysis of middle-income countries. J Int
Trade Econ Dev 28(3):317–330
Mahmood A, Marpaung CO (2014) Carbon pricing and energy effi-
ciency improvement–why to miss the interaction for developing
economies? An illustrative CGE based application to the Paki-
stan case. Energy Policy 67:87–103
Mohsin M, Kamran HW, Nawaz MA, Hussain MS, Dahri AS (2021)
Assessing the impact of transition from nonrenewable to renew-
able energy consumption on economic growth-environmental
nexus from developing Asian economies. J Environ Manag
284https:// doi. org/ 10. 1016/j. jenvm an. 2021. 111999
Muhammad S, Long X (2021) Rule of law and CO2 emissions: a com-
parative analysis across 65 belt and road initiative (BRI) coun-
tries. J Clean Prod 279:123539
Nasir M, Rehman FU (2011) Environmental Kuznets curve for car-
bon emissions in Pakistan: an empirical investigation. Energy
Policy 39(3):1857–1864
Nasreen S, Mbarek MB, Atiq-ur-Rehman M (2020) Long-run causal
relationship between economic growth, transport energy con-
sumption and environmental quality in Asian countries: Evi-
dence from heterogeneous panel methods. Energy 192:116628
Nawaz MA, Hussain MS, Kamran HW, Ehsanullah S, Maheen R,
Shair F (2021a) Trilemma association of energy consumption,
carbon emission, and economic growth of BRICS and OECD
regions: quantile regression estimation. Environ Sci Pollut Res
28(13):16014–16028
Nawaz MA, Seshadri U, Kumar P, Aqdas R, Patwary AK, Riaz M
(2021b) Nexus between green finance and climate change mit-
igation in N-11 and BRICS countries: empirical estimation
Environmental Science and Pollution Research
1 3
through difference in differences (DID) approach. Environ
Sci Pollut Res 28(6):6504–6519. https:// doi. org/ 10. 1007/
s11356- 020- 10920-y
Omri A, Hadj TB (2020) Foreign investment and air pollution: do
good governance and technological innovation matter? Environ
Res 185:109469
Othman Z, Nordin MFF, Sadiq M (2020) GST fraud prevention to
ensure business sustainability: A Malaysian case study. J Asia
Bus Econ Stud 27(3):245–265
Ozturk I, Al-Mulali U (2015) Investigating the validity of the envi-
ronmental Kuznets curve hypothesis in Cambodia. Ecol Ind
57:324–330
Pesaran MH (2007) A simple panel unit root test in the presence of
cross-section dependence. J Appl Economet 22(2):265–312
Pesaran MH (2015) Testing weak cross-sectional dependence in large
panels. Economet Rev 34(6–10):1089–1117
Pesaran MH, Yamagata T (2008) Testing slope homogeneity in large
panels. J Econom 142(1):50–93
Sadiq M, Hsu CC, Zhang Y, Chien FS (2021a) COVID-19 fear and
volatility index movements: empirical insights from ASEAN
stock markets. Environ Sci Pollut Res. https:// doi. org/ 10. 1007/
s11356- 021- 15064-1
Sadiq M, Nonthapot S, Mohamad, Keong OC, Ehsanullah S, Iqbal N
(2021b) Does Green Finance Matters for Sustainable Entrepre-
neurship and Environmental Corporate Social Responsibility
during Covid-19? China Finance Rev Int. https:// doi. org/ 10.
1108/ CFRI- 02- 2021- 0038
Sadiq M, Alajlani S, Hussain MS, Ahmad R, Bashir F, Chupradit
S (2021c) Impact of credit, liquidity, and systematic risk on
financial structure: comparative investigation from sustainable
production. Environ Sci Pollut Res. https:// doi. org/ 10. 1007/
s11356- 021- 17276-x
Salahuddin M, Alam K, Ozturk I, Sohag K (2018) The effects of elec-
tricity consumption, economic growth, financial development
and foreign direct investment on CO2 emissions in Kuwait.
Renew Sustain Energy Rev 81:2002–2010
Saleem H, Khan MB, Shabbir MS (2020) The role of financial develop-
ment, energy demand, and technological change in environmen-
tal sustainability agenda: evidence from selected Asian countries.
Environ Sci Pollut Res 27(5):5266–5280
Santra S (2017) The effect of technological innovation on production-
based energy and CO2 emission productivity: evidence from
BRICS countries. Afr J Sci Technol Innov Dev 9(5):503–512
Sathaye J, Gupta A (2010) Eliminating electricity deficit through
energy efficiency in India: an evaluation of aggregate economic
and carbon benefits: Lawrence Berkeley National Lab.(LBNL),
Berkeley, CA (United States).
Schmidt P, Phillips PC (1992) LM tests for a unit root in the presence
of deterministic trends. Oxford Bull Econ Stat 54(3):257–287
Shahbaz M, Hye QMA, Tiwari AK, Leitão NC (2013) Economic
growth, energy consumption, financial development, interna-
tional trade and CO2 emissions in Indonesia. Renew Sustain
Energy Rev 25:109–121
Shahbaz M, Khraief N, Uddin GS, Ozturk I (2014) Environmental
Kuznets curve in an open economy: a bounds testing and causal-
ity analysis for Tunisia. Renew Sustain Energy Rev 34:325–336
Shahbaz M, Raghutla C, Song M, Zameer H, Jiao Z (2020) Public-
private partnerships investment in energy as new determinant of
CO2 emissions: the role of technological innovations in China.
Energy Econ 86:104664
Shair F, Shaorong S, Kamran HW, Hussain MS, Nawaz MA (2021)
Assessing the efficiency and total factor productivity growth of
the banking industry: do environmental concerns matters? Envi-
ron Sci Pollut Res 28(16):20822–20838
Shao X, Zhong Y, Liu W, Li RYM (2021) Modeling the effect of green
technology innovation and renewable energy on carbon neutrality
in N-11 countries? Evidence from advance panel estimations. J
Environ Manag 296:113189
Sun H, Awan RU, Nawaz MA, Mohsin M, Rasheed AK, Iqbal N (2020)
Assessing the socio-economic viability of solar commercializa-
tion and electrification in south Asian countries. Environ Dev
Sustain 1-23https:// doi. org/ 10. 1007/ s10668- 020- 01038-9
Swamy PA (1970) Efficient inference in a random coefficient regression
model. Econom: J Econom Soc, 311–323.
Tachie AK, Xingle L, Dauda L, Mensah CN, Appiah-Twum F, Men-
sah IA (2020) The influence of trade openness on environ-
mental pollution in EU-18 countries. Environ Sci Pollut Res
27(28):35535–35555
Tan LP, Sadiq M, Aldeehani TM, Ehsanullah S, Mutira P, Vu HM
(2021) How COVID-19 induced panic on stock price and green
finance markets: global economic recovery nexus from volatil-
ity dynamics. Environ Sci Pollut Res. https:// doi. org/ 10. 1007/
s11356- 021- 17774-y
Wang J, Lv K, Bian Y, Cheng Y (2017) Energy efficiency and marginal
carbon dioxide emission abatement cost in urban China. Energy
Policy 105:246–255
Westerlund J, Edgerton DL (2008) A simple test for cointegration in
dependent panels with structural breaks. Oxford Bull Econ Stat
70(5):665–704
Xiang H, Ch P, Nawaz MA, Chupradit S, Fatima A, Sadiq M (2021)
Integration and economic viability of fueling the future with
green hydrogen: An integration of its determinants from renew-
able economics. Int J Hydrogen Energy. https:// doi. org/ 10. 1016/j.
ijhyd ene. 2021. 09. 067
Xueying W, Sadiq M, Chien F, Ngo TQ, Nguyen AT (2021) Testing
role of green financing on climate change mitigation: Evidences
from G7 and E7 countries. Environ Sci Pollut Res 28(47):66736–
66750. https:// doi. org/ 10. 1007/ s11356- 021- 15023-w
Yii K-J, Geetha C (2017) The nexus between technology innovation
and CO2 emissions in Malaysia: evidence from granger causality
test. Energy Procedia 105:3118–3124
Yu Y, Du Y (2019) Impact of technological innovation on CO2 emis-
sions and emissions trend prediction on ‘New Normal’economy
in China. Atmos Pollut Res 10(1):152–161
Zameer H, Yasmeen H, Zafar MW, Waheed A, Sinha A (2020) Analyz-
ing the association between innovation, economic growth, and
environment: divulging the importance of FDI and trade open-
ness in India. Environ Sci Pollut Res 27:29539–29553
Zhao L, Zhang Y, Sadiq M, Hieu VM, Ngo TQ (2021) Testing green
fiscal policies for green investment, innovation and green pro-
ductivity amid the COVID-19 era. Econ Chang Restruct. https://
doi. org/ 10. 1007/ s10644- 021- 09367-z
Zhang S, Liu X, Bae J (2017) Does trade openness affect CO 2 emis-
sions: evidence from ten newly industrialized countries? Environ
Sci Pollut Res 24(21):17616–17625
Zhuang Y, Yang S, Chupradit S, Nawaz MA, Xiong R, Koksal C (2021)
A nexus between macroeconomic dynamics and trade openness:
moderating role of institutional quality. Bus Process Manag J.
https:// doi. org/ 10. 1108/ BPMJ- 12- 2020- 0594
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