Abstract
We empirically investigate the linkages between income inequality and the shadow economy. Employing a panel vector autoregression model, we build impulse response functions to study the time path of income inequality following a shock to the shadow economy, and vice versa. Our results using panel data for 144 countries over the period 1960–2009 reveal a bidirectional positive relationship between the two: specifically, higher income inequality promotes the spread of the shadow economy while the development of the shadow economy contributes to income inequality. Overall, these findings withstand a variety of robustness checks.
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Notes
The relationship between inequality and growth may depend on the level of development as described by the infamous Kuznets curve (see Kuznets 1955).
Z. M. Beddoes, “For richer, for poorer”, The Economist, 13 October 2012.
The shadow economy includes economic activity that is unregistered in the official economy.
Previous studies that examine the relationship between growth and inequality focus on only one sector of the economy, that is, the official sector, while neglecting the unofficial sector. Indeed, Schneider (2005, 2010) argued that the official economy could never run efficiently without the unofficial economy. Therefore, the shadow economy could be the missing link to better understand the ambiguous relationship between inequality and growth in the official economy.
Furthermore, Chong and Gradstein (2007, p. 165) argue that “this effect is magnified by poor institutional quality, which enhances the difference in rent seeking investments between the rich and the poor.”
See also Kim (2005) who shows that lower income participants are more likely to operate in the shadow sector.
Before estimation, it is imperative to test the stationarity properties of the data. To do this we used the Fisher-type panel unit root test based on the Phillips–Perron test under the null hypothesis that all panels contain a unit root against the alternative that at least one panel is stationary (with and without correcting for cross-sectional dependence). Based on the inverse Chi-squared test, the null hypothesis is rejected for each variable. These results are available upon request.
This transformation is also useful when the dataset contains many missing values.
With an unrestricted maximum lag length the AIC (BIC) chooses 16 (9) lags resulting in 144 (81) parameters to be estimated. Therefore, to prevent this overparameterization, we restrict the maximum lag length to 3.
The observations vary across the different models estimated depending on data availability.
As a word of caution, our main shadow measure is indirectly a function of GDP; however, the use of lagged values in the panel VAR models mitigates problems with this sort of identification issue.
For a fascinating and comprehensive review of entrepreneurship and the “hidden enterprise culture” in the informal economy, see Williams (2006).
The coefficient estimates are likely highly collinear; thus, the reader is advised to exercise caution when interpreting these results (see Enders 2010).
Readers are encouraged to exercise caution when interpreting the results as there is likely inequality present within the shadow economy as well. We thank an anonymous referee for pointing this out.
In addition to the following robustness checks, we also checked to ensure our results were not sensitive to the global shock related to the Great Recession (2008–2009). To do this, we restricted the time period to 1960–2007 and re-estimated the baseline model. These results are consistent with our baseline results and available upon request.
Furthermore, we account for the influence of tax revenue (as a percent of GDP) from the World Development Indicators of the World Bank (2015). Specifically, we re-estimate Eq. (1) with the vector Y containing the following variables (in specific causal ordering): lgdp, tax, inequality (market), and shadow. We also include inequality (net) in place of inequality (market) in the system. The impulse response functions illustrate that income inequality promotes the shadow economy (particularly in the system that includes inequality (net)) while the reverse effect is insignificant. These results are available upon request.
We also employed an alternate measure of institutional quality, specifically a measure of democracy from Marshall et al. (2017). The impulse response functions continue to show a positive bidirectional relationship between income inequality and the shadow economy. These results are available upon request.
We also considered the measure of the shadow economy by Alm and Embaye (2013) using the currency demand approach. While the positive effect of the shadow on inequality is present, the effect of inequality on the shadow economy is actually negative and significant. This difference is likely because this measure is most closely tied to the use of cash underground, whereas the other two measures can be viewed as more broad measures of shadow activities (e.g., including barter). These results are available upon request.
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Acknowledgements
We thank Cynthia Bansak (editor), four anonymous referees, and participants at the Midwest Economics Association Conference (Cincinnati), Western Economic Association International Conference (San Diego), 5th International Conference on “The Shadow Economy, Tax Evasion and Informal Labor” (Warsaw) and International Atlantic Economic Conference (Montréal) for valuable suggestions. All remaining errors are our own.
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Berdiev, A.N., Saunoris, J.W. On the Relationship Between Income Inequality and the Shadow Economy. Eastern Econ J 45, 224–249 (2019). https://doi.org/10.1057/s41302-018-0120-y
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DOI: https://doi.org/10.1057/s41302-018-0120-y