Abstract
The reduction of \(\hbox {CO}_2\)emissions has been at the centre of worldwide debates on environmental issues, though its inclusion as one of the millennium development goals (MDGs) by the United Nations has changed the focus of relative literature. Among many, one of the World Bank’s “recipes” to achieve a higher position toward MDGs has been to undertake reforms for a better governance. While, the majority of researches’ focus has been on one single aspect and its relationship with the environment, some studies, have simultaneously considered two governance dimensions. In this paper, we focus on the role of several aspects of governance on \(\hbox {CO}_2\)emissions. This provides us with a chance to explore the possible impacts of all aspects of governance on a more direct measure of emissions, that is different to previous researches which have focused on the indirect transmission and considered the maximum of two. Using the IV method within panel data analysis, we show that only one single aspect of governance, Control of Corruption, has a negative significant effect on \(\hbox {CO}_2\)emissions and its effect has a non-linear relationship. The non-linearity exists in both parametric and nonparametric analysis after controlling for endogeneity.
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Notes
Developed by Esty et al. (2006).
However, researches such as Moomaw and Unruh (1997) and other argue existence of such an effect and EKC.
i.e., Six aspects of governance or World Governance Indicators that ar developed by Kaufmann et al. (1999).
Wikipedia states that the ‘ISO 14001 sets out the criteria for an Environmental Management System (EMS). It does not state requirements for environmental performance, but maps out a framework that a company or organisation can follow to set up an effective EMS. It can be used by any organisation that wants to improve resource efficiency, reduce waste, and drive down costs. Using ISO 14001 can provide assurance to company management and employees as well as external shareholders that environmental impact is being measured and improved. ISO 14001 can also be integrated with other management functions and assists companies in meeting their environmental and economic goals’.
As discussed earlier, there are a number of nonparametric estimators for fixed effects panel data and to address the discussions on the selection of estimators and confirm the robustness of the results, in “Appendix 1.5” a recent development in nonparametric estimators in the panel data, Pütz and Kneib (2016), is briefly described and relevant results are presented.
See (Henderson and Parmeter 2015, p. 295, 301).
More specifically Su and Lu (2013), Su and Zhang (2015) assumed that the vector of exogenous X enters in nonparametric section of the model along with lagged value of dependent variable and therefore the model named Dynamic Panel [See (Su and Lu 2013, p. 2) and (Su and Zhang 2015, p. 2)]. Such specification is different than other methods known dynamic panels such as System GMM Dynamic panel Data, in which variables and their differences are lagged and used as instruments. Similarly, in Cai and Li (2008) where authors proposed a nonparametric estimator for varying coefficients in panel data, it is assumed that the nonparametric component of the model is exogenous. (See the text introducing the main equation in Cai and Li (2008)). Exogeneity assumption of X seems inevitable to avoid the ill-posed inverse problem (Su and Zhang 2015). Nevertheless, this branch of literature is still growing and some recent publications such as Cazals et al. (2016), Delgado et al. (2015) have explored more avenues to address this problem
Pellegrini and Gerlagh (2006)’s main equation estimated the urban growth rate and schooling of adults who had completed secondary school.
For more detailed results of the two-way fixed effect regression see “Appendix 1.2”.
\({\hat{{\textit{CC}}}}^{2}\) is the predicted values from the first regression of TSLS in Panel data where the endogenous variables is in LHS and IV is in RHS.
Trade Openness data is available from IMF and the World Bank web sites. The ratio of export of Raw Material was calculated based on the values access from the World Bank database. ELF index was proposed by Mauro (1995b) and has been used in several works. More details on these variables can be obtained from Seldadyo and Haan (2006).
It should be noted that the assumption of linear relationship between \(\nu \) and \(\epsilon \) is crucial for this solution and in this study such an assumption does not seem to be restrictive nor does impractical.
\(\nu \) is the residuals of equation \(z=W \pi + \nu \).
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The author would like to thank Prof. Alan Duncan, Dr. Astghik Mavisakalyan and two anonymous referees for their helpful comments and suggestions. Errors are mine.
Appendices
Appendix 1
Appendix 1.1: Variables Definition and Data Source
See Table 4.
1.1 Appendix 1.2: Countries in the Sample
See Table 5.
1.2 Appendix 1.3: Two Way Fixed Effects Regression
See Table 6.
1.3 Appendix 1.4: Details of the Solution for Endogeneity in Semi-Parametric Regression
Following proofs are from Vincenzo Verardi (author of relevant Stata package) presentation in 2013 UK Stata Users Group meeting.
In Standard IV, the variable X is called endogenous when in \(y=X \beta + \epsilon \) it is possible to show that \(E(\epsilon | X) \ne 0\). As a solution an exogenous variable(\(\backslash \)Instrument) W is found and therefore the estimated coefficient would be \(\hat{\beta _{IV}}=\left( X'P_{w} X \right) ^{-1} X'P_{w}y \) in which \(P_{w}=W(W'W)^{-1}W'\) is the part of endogenous variable that can be explained by the instrument (i.e. W). In other words, \(P_{w}\) is the fitted values of \(X=W+\nu \). And by using the IV the equation would be \(y=X \beta + + \gamma {\hat{\nu }} + \epsilon \) (CFA).
However, in Semi-parametric, where the equation can be presented as \(y=X \beta + m(z)+ \epsilon \), if \(E(\epsilon | X) = 0\) and \(E(\epsilon | z) \ne 0\) finding the a solution can be complicated and difficult. To explain the source of difficulty, take the expected value from the equation, condition on z : \(E(y|z)=E(X|z) \beta + m(z)+\underbrace{E(\epsilon | z)}_{\ne 0 }\). Because z is endogenous it is impossible to efficiently estimate the E(y | z) and E( X |z).
However, if we find a variable W that is correlated to z and not \(\epsilon \) and have \( z= W \pi + \nu \) and \(E(\nu | W)= 0\). Then if we assume that there is a linear relationship between \(\nu \) and \(\epsilon \) such as \(\epsilon = \rho \nu + \eta \).Footnote 17
With this new notations, the main equation would be \(y=X \beta + + m(z) + \rho \nu + \eta \) Footnote 18 and can be estimated using the semi-parametric method.
1.4 Appendix 1.5: Nonparametric Estimates of \(\theta (\cdot )\) with the Actual Values
See Fig. 6.
1.5 Appendix 1.6: A New Nonparametric Estimator in Fixed Effects Panel Data
The earlier estimator by Baltagi and Li (2002), Verardi and Libois (2012) which used series estimation of B-Splines of a single nonparametric variable was used in several studies such as Desbordes and Verardi (2012). However, the recent estimator by Pütz and Kneib (2016) accommodates a multidimensional nonparametric estimator, by penalizing the splines for each nonparametric variable. In order to show the robustness of the results with regard to recent development and the choice of model and estimator, in this section the model is estimated assuming the only variables that are considered as nonparametric are CC and LGDPPC (following EKC literature). In this settings, the rest of variables assumed to have a linear function. As illustrated by Fig. 7, despite the relatively larger dispersion the general results are consistent. Another interesting aspect of the results, shown in Table 7, is the close estimates of variables to their parametric counterparts in Table 3.
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Tarverdi, Y. Aspects of Governance and \(\hbox {CO}_2\)Emissions: A Non-linear Panel Data Analysis. Environ Resource Econ 69, 167–194 (2018). https://doi.org/10.1007/s10640-016-0071-x
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DOI: https://doi.org/10.1007/s10640-016-0071-x