Abstract
Prior studies obtained mixed conclusions on the relationship between firm exporting and pollution emissions, probably because the role of environmental regulation has been ignored in this relationship. This study focuses on whether the abatement effect of exporting is related to the stringency of environmental regulation. To avoid measurement bias in the environmental regulation stringency faced by firms, we use the two control zones policy implemented in China to reduce sulfur dioxide (SO2) emissions as a natural experiment to distinguish the difference in the SO2 regulation stringency faced by different firms. Empirical results show that Chinese manufacturing firms can significantly reduce their SO2 emissions intensity by exporting, but the abatement effect of exporting occurs only in the firms regulated by the two control zones policy. This result confirms for the first time that the abatement effect of exporting stems from the incentives of stringent environmental regulations. Further analysis shows that the abatement effect of exporting is realized mainly through firm investment in source control technologies rather than in end-of-pipe treatment technologies. The findings of this study suggest that stringent environmental regulations are important for emerging and developing countries to achieve environment-friendly exports.
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Some or all data, models and/or code generated or used during the study are available from the corresponding author upon request.
Notes
A region is included in an SO2 pollution control zone if (1) the annual average concentration of SO2 in its environment exceeded the national secondary standard in recent years, (2) the daily average concentration of SO2 in its environment exceeds the national tertiary standard (i.e., 250 μg/m3), or (3) its SO2 emissions are significant. A region is included in an acid rain control zone if (1) the average value of potential of hydrogen in its precipitation is equal to or less than 4.5, (2) its sulfate deposition exceeds the critical load, or (3) its SO2 emissions are large. For details, see https://www.mee.gov.cn/.
The TCZs policy focuses on controlling SO2 emissions from coal combustion using comprehensive prevention and control measures combining industrial restructuring, energy conservation, and consumption reduction, changing the urban energy structure, promoting clean production, and eliminating outdated processes and equipment with end-of-pipe treatment.
In the literature on the relationship between firm exporting and firm economic performance, scholars used different methods to test how exporting benefits firms. So far however, there remains to be a unified conclusion on which method is better. For example, Chang & Chung (2017) used several methods examined learning-by-exporting hypothesis, and pointed out that “Since each approach is based on its own theoretical assumptions and data requirements, we cannot say whether one approach is superior. Rather, each approach is best suited to particular settings, data, and phenomena”.
The value added is deflated by the industry-level (four-digit Chinese industry classification) producer price index. The addition of one before the logarithm is taken is performed to retain the firms with zero SO2 emissions in the study sample. However, regardless of the environmental regulation stringency for SO2 emissions, the firms with no SO2 emissions have no incentive to reduce such emissions. Therefore, in the robustness tests, the firms with no SO2 emissions are removed from the sample.
The Sargan–Hansen test is as a generalized test for over-identifying restrictions between fixed and random effects of a panel data model, which is generated in STATA using the—xtoverid—command. Unlike the Hausman version, the xtoverid enabled us to use the coefficients of the cluster-robust panel regression.
Fixed assets are deflated by the fixed asset price index.
Lin (2015) compared the annual growth rate of the Baltic Dry Index with the growth in average exports volume for China’s exporters and found that the growth (decline) in the Baltic Dry Index is at times accompanied by a slowdown (expansion) in exports over the period from 1999 to 2007.
Lin & Sim (2013) showed that country groups, such as the least developed countries, are insignificant in driving the Baltic Dry Index, let alone a firm.
The sample includes only firms with more than three years of records between 2000 and 2007 to avoid estimation bias owing to the short observation period.
\({S}_{i,0}=(sal{e}_{i,0}-\mathit{min}\_sal{e}_{i\in j,0})/(\mathit{max}\_sal{e}_{i\in j,0}-\mathit{min}\_sal{e}_{i\in j,0}),{S}_{i,0}\in ({0,1}]\), where \(sal{e}_{i,0}\) is the total sales of firm i in the base year, and \(\mathit{max}\_sal{e}_{i\in j,0}\) and \(\mathit{min}\_sal{e}_{i\in j,0}\) are the maximum and minimum total sales of the firms in industry j (the two-digit industry to which firm i belongs) in the base year, respectively. The base year is set to 1999.
Lin (2015) use \({\theta }_{i,0}\times \text{ln}(BD{I}_{t-1})\) as an instrumental variable for the export value of Chinese firms during the period of 2000–2007. Since existing research suggested that the sunk costs of firms to enter export markets are high, and firms with considerable capacity can effectively bear the fixed costs of exporting (Melitz, 2003), we modify the instrumental variable in Lin (2015) by adding the multiplier \({S}_{i,0}\).
Integrated prevention and control measures for acid rain and SO2 emissions in TCZs mainly include (1) reducing the sulfur content of coal, (2) controlling SO2 emissions from thermal power plants, (3) controlling SO2 emissions from boilers, (4) controlling SO2 emissions from industrial furnaces, (5) strengthening the construction of urban energy infrastructure to control domestic SO2 emissions, and (6) controlling SO2 emissions from various processes. See https://www.mee.gov.cn/gkml/zj/wj/200910/t20091022_172128.htm for details.
For example, if more zero-emissions firms are distributed in NTCZs than in TCZs, then observing the abatement effect of exporting in the NTCZs may be difficult.
PSM-DID is generally used in studies on the relationship between firms’ export strategies and economic performance.
To calculate the emissions intensity changes in the treatment group before and after exporting (see the first item in brackets in Equation [5]), we must include the firms with continuous observations (i.e., the emissions data and export status can be observed year by year) and an export status changing from 0 to 1 into the treatment group. However, owing to the data structure problem, the number of firms meeting the above conditions is limited. For example, some firms start to export in year t, but their emissions data in year t-1 or year t are missing. We can observe the emissions data in the second and third years after exporting for only a few firms. Therefore, to accurately estimate and alleviate the estimation error caused by the small sample size, we keep the observation in the year when the firm starts to export and the observation in the previous year of exporting and use PSM-DID to analyze the short-term effects of exporting on SO2 emissions intensity.
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Acknowledgements
This paper was supported by the Science Foundation of Ministry of Education of China [grant number: 18XJA790008], and the Fundamental Research Funds for the Central Universities [grant number: JBK230117; JBK2307119].
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Appendices
Appendix A
We conducted some tests to ensure that fixed effect estimation is appropriate for our models. The simple way to check for the fit of fixed effects model is to use the Hausman test to compare the standardized regression coefficients of the fixed effects model with those of the random effects model. However, the Hausman test does not allow for cluster-robust standard errors and thus could not control for the unobserved heterogeneity of firms. Hence, we used an alternative Hausman-like test (i.e., the xtoverid cluster test) to compare fixed vs. random effects (Schaffer & Stillman, 2016). Sargan–Hansen tests were performed following the specifications in Columns (4) to (6) of Table 2. The Sargan–Hansen test shows that the p-value of the Chi-square is less than 0.05, thereby indicating that the null hypothesis is rejected and that fixed effects estimator is an appropriate estimator for our regression models. Details can be found in Table
10.
Appendix B
Tables 11, 12, 13, 14 show the first- and second-stage regression results of the 2SLS estimation obtained through the Stata command xtivreg2. The estimation results of the first-stage regression in Tables 11, 12, 13 and 14 show that the coefficients of the instrumental variable BDIf are significantly negative, thereby indicating that the higher the Baltic Dry Index faced by firms, the lower their likelihood of exporting. This outcome is consistent with our expectation of the negative effect of the Baltic Dry Index on firms’ export decisions owing to trade costs.
Appendix C
See Table 15.
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Cheng, R., Yuan, P. & Li, H. Abatement effect of exporting and environmental regulation stringency: evidence from a natural experiment in China. Environ Dev Sustain (2023). https://doi.org/10.1007/s10668-023-03564-8
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DOI: https://doi.org/10.1007/s10668-023-03564-8