Abstract
Economic theory postulates that taxes and alternative tax policies have different impacts on economic growth. Some scholars have argued that economic growth can result in an increase in total tax revenues and its ratio to GDP. Our study investigates the impact of economic growth on total tax revenues and different tax share ratios in transitional economies. We find strong support for the hypothesis that economic growth leads to an increase in total tax revenue-to-GDP ratio. We also find that economic growth has led to, and facilitated, changes in the relative shares of different tax sources in transition countries over time differently thus allowing these countries to streamline their taxes and properly plan for and alter their tax system accordingly.
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Additional information on data and sources of data are available from the authors upon request.
Notes
To calculate real openness, the following formula, proposed by Alcala and Ciccone (2004: 613) was utilized: \(Real Opennes{s}_{AC}=\frac{Imports \left(\$\right)+Exports (\$)}{GDP PPP, \$}\).
We ran instrumental-variable GMM estimations to ensure robustness of our results. Taking first differences we obtain dynamic model: $$\Delta ln\text{ }{\tau }_{it}={\beta }_{0}+{\beta }_{1}\text{\Delta }\mathit{ln} {Y}_{it-1}+{\sum }_{i,t=1}^{k}{\eta }_{i}{\text{\Delta }Z\text{'}}_{i, t-1}+({\alpha }_{i}-\text{ }{\alpha }_{i})+\text{\Delta }{\varepsilon }_{it}$$. To find a set of instruments that satisfy $$E\left({Z}_{it}\text{\Delta }{\varepsilon }_{it}\right)=0$$, in addition to using all available lag levels for the first difference equation as per Arellano and Bond (1991), we constructed Anderson-Hsiao estimator to the first-differenced equation, instrumenting the lagged dependent variable with the twice-lagged level: $${\tau }_{i(t-2)}$$ and $$\Delta {\tau }_{i(t-2)}$$ as per Judson and Owen (1999). The estimations of extended models for difference GMM and system GMM are reported in Appendix II.
While we kept fixed-effects (within) regression with robust standard errors clustered at the country level as our baseline model estimation, our extended model relied on first difference GMM and system GMM transformation as in our panel sample T < N, i.e. fewer time periods than number of countries.
Election year is defined as an election year of either president or a prime-minister, or whoever of these two posts who acts as a head of state in our sample of countries.
Abbreviations
- CIT:
-
Corporate Income Tax
- HIC:
-
High-income countries
- FEM:
-
Fixed-effect model
- GDP:
-
Gross Domestic Product
- GNP:
-
Gross National Product
- LIC:
-
Low-income countries
- MIC:
-
Middle-income countries
- OECD:
-
Organization for Economic Cooperation and Development
- PIT:
-
Personal Income Tax
- SSC:
-
Social Security Contributions
- VAT:
-
Value-Added Tax
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We are grateful to two anonymous reviewers of the journal for their constructive comments and suggestions on the earlier version of this article.
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Appendices
Appendix 1: Descriptive statistics and data definition
Appendix 2: Results of diagnostic tests to ensure robustness of the empirical model
Please refer to footnotes 1 and 2 in the text for additional background on these results (Tables 6, 7).
Appendix 3: The stationarity of tax variables and adf-unit root test results
To check for stationarity (or unit roots) of tax variables and GDP per capita growth in our panel dataset, the Fisher type panel-data unit-root tests are performed. Fisher-type unit-root tests for all tax and GDP variables are based on (a) Augmented Dickey-Fuller (ADF) test and (b) Phillips-Perron (PP) test. The null hypothesis of both the Fisher-ADF and the Fisher-PP unit root tests is that all panels contain a unit root or stationarity. The alternative hypothesis of the tests is that at least one panel is stationary. Panel-specific means (fixed effects) in the model are included, but time trend is excluded.
Lags (5) of the series are used in the Fisher-ADF and Fisher-PP regressions. The lags (5) are used to remove higher-order autoregressive components of the series. Thus, the assumption is that the data are generated by AR (5) process for Fisher tests:
The results of this test for all the tax variables and GDP per capita growth are given in Table 8. The first noticeable thing in this table is that almost all the estimated coefficients are individually highly significant, for the p-values are low. This gives us strong evidence against the null hypothesis in favor of the alternative (as p-values are mostly within the range of 0.001 < p < 0.01). These results confirm that the GDP per capita growth and tax variables are all stationary in their change or difference form.
Furthermore, the test results indicate that all our dependent and explanatory variables in panel are stationary. Almost all variables in first differences pass the stationarity test at 1% significance level.
Appendix 4: Omitted variables test (model with political budget cycle and year of accession to the eu dummy variables)
To ensure that missing variable phenomenon has not biased the empirical results of our main regression models, we have deployed four dummies as proxies. For political budget cycle we use: (1) one year before election yearFootnote 4; (2) one year after election year; proxy for specific tax policies adopted by countries at different point in time. For membership in the European Union (EU) we use two dummies, namely—(3) year of EU accession; and (4) one year after EU accession, controlling for country fixed effects and time dummies.
When running regression with these dummies, we used one fewer dummy than the number of categories for any categorical variable to avoid collinearity using the following model:
Then, we leave the intercept in (5) to make the model more robust and to obtain unbiased standard errors:
where \({D}_{1i}=\text{PB }(\text{one year before election year dummy})\), \({D}_{2i}=PB+1 (\text{one year after election year dummy})\), \({D}_{3i}=\text{EU }(\text{EU accession year dummy})\), \({D}_{4i}=EU+1 (\text{one year after EU accession year dummy})\).
Equation (7) with added dummy variables is integrated with the tax structure grand regression (the main regression in columns 1 of Table 9 when re-running the model below:
The regression results for Eq. (8) are presented in Table 9 below.
First and foremost, when comparing the results in Table 9 with those in column 1 of Table 5, the signs and significance of estimated coefficients for all the original explanatory variables are the same. These results confirm that our original model is robust in explaining the trends in overall tax revenues of the transition economies and new variables do not alter the conclusions arrived at based on that model. Nonetheless, introduction of both political budget cycle and year of membership in the EU dummies produce valuable information.
Specifically, the results in columns 1–4 of Table 9 suggests that the political budget cycle instruments represented in the form of dummy variables \({D}_{1i} \text{one year before election year}\) has a negative impact on tax revenue collection overall when a one-year pre-election year is plagued by political manipulation due to political budget cycle theory (Ferraressi 2021; Golden and Min, 2013). Consequently, fiscal tools such as overall tax revenues and various types of taxes are negatively affected. In contrast to that, \({D}_{2i}\) one year after election variable, has a positive and highly significant impact on the tax revenue collection, suggesting that after election to their respective office, political leaders tend to deviate from their tax reduction promises during the election and raise taxes.
The EU membership dummy variable \({D}_{3i}\) year of EU accession has a negative effect on collection of tax revenues in our sample, suggesting slightly lower revenues compared to the pre-accession period for new EU members. Such a decrease in tax revenues may suggest elimination of tax sources that were previously collected through the local channels that could not continue after EU accession. However, \({D}_{4i}\) one year after EU accession, shows a positive impact on overall tax collection for new EU member countries. This may be due to introducing new tax policies and tax sources to comply with the EU common fiscal regime.
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Khujamkulov, I., Abizadeh, S. Trends in tax revenues of transition economies: an empirical approach. Empir Econ 64, 833–868 (2023). https://doi.org/10.1007/s00181-022-02269-7
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DOI: https://doi.org/10.1007/s00181-022-02269-7