Abstract
This paper examines the sensitivity of marginal tax reform analysis to changes in the underlying demand system. In particular, we analyse the sensitivity of results from Ahmad and Stern’s (J Publ Econ 25(3):259–298, 1984) marginal tax reform model to different specifications of Deaton and Muellbauer’s (Am Econ Rev 70(3):312–326, 1980) Almost Ideal Demand System (AIDS) and Banks et al.’s (Rev Econ Stat 79(4):527–539, 1997) Quadratic AIDS. Using Irish Household Budget Survey data, we show that tax reform results exhibit a low degree of sensitivity to changes in the underlying demand system. An adjustment for a mass of observed zero-expenditures in the data for certain goods produces most sensitivity in the tax reform results. Even in these cases, many of the tax reform recommendations remain constant. Including demerit good arguments in the tax reform model can substantially alter the tax reform recommendations relating to demerit goods. Notably though, when we include these arguments in the tax reform model, the results are particularly insensitive to changes in the underlying demand system.
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Notes
Ahmad and Stern calculate the marginal social cost (\(MSC\)) of taxation. Due to commodity- specific Laffer effects, Madden (1995a) recommends using the MRC, where \(MRC=1/MSC\). See Appendix for details.
Or a welfare-neutral revenue-improving change.
Full derivation presented in appendix.
The equivalence scale used here is the national scale used by the Central Statistics Office (CSO) and closely matches that implicit in the Irish welfare system. The scale is 1 for the first adult, 0.66 for subsequent adults and 0.33 for children.
The poorest household in this paper is defined as the household with the lowest equivalised expenditure.
Determined by the sensitivity of the ranking of goods by \(MRC\).
Here we use unequivalised expenditure. This allows use to include demographics in the system, as detailed in the next section.
The demographics in the model are : age of head of household (HoH) and spouse, number of persons in the household, sex HoH, an urban/rural identifier and quarter. Alternative sets of demographics included percentage of income up made in state transfers, household composition and household tenure, with little sensitivity in the resulting elasticities.
Applied in Stata by Poi (2012).
Given the specification of the demand equation in the second step of Shonkwiler and Yen’s approach, the adding-up assumption (see Eq. 14) is violated. In order to retain this assumption, we follow Yen et al. (2003) so that the final equation in the 6-good system is estimated with \(w_{6}= 1-\sum \nolimits _{i=1}^{5}w_{i}\). See Yen et al. (2003), and Zheng and Henneberry (2010) for an empirical application.
Pre-1995, the survey was conducted every 7 years.
Specifically, we use the 1987, 1994/1995, 1999/2000, 2004/2005 and 2009/2010 waves of the HBS.
We use the CSO national equivalence scale of 1 for the first adult, 0.66 for subsequent adults, and 0.33 for children.
Elasticities were also estimated using December 2006 as the base time period, with very similar results.
The tax rate includes value-added tax (VAT) and excise duty.
The Engel curves are estimated using a Gaussian Kernel.
Curvature of the Engel curves suggests using the QUAIDS model rather than the AIDS model—see Sect. 2.3.
For the sake of brevity, the elasticities presented here elasticities estimated at sample means. In the \(MRC\) analysis in the next section, we estimate separate elasticities for each of the years of analysis.
Recall, these elasticities are averages over each of the years in the analysis. The own-price elasticity of food, for example, ranges from \(-\)0.3 in 1987 to 0.2 in 2009 under the PS-QUAIDS model.
This table compares the budget elasticities and cross-price elasticities of the PS-AIDS and PS-QUAIDS models. The unadjusted models and zero-expenditure adjusted models result in similar comparisons.
In other words, if tobacco was still the lowest ranked \(MRC\) good, the other rankings changed accordingly.
Strictly, the rankings in Madden (1995a) are based on elasticities from a D-AIDS model (AIDS model estimated in first differences). Here we compare Madden’s \(MRC\) ranking that was based on the AIDS model, as in this paper, which was obtained through personal correspondence with the author.
See Appendix for the rankings of the goods.
The higher tax on saturated fat was abolished 15 months after its introduction.
The scale elasticity can be interpreted as the relative change in the demand price of commodity \(j\) due to a 1 % increase in the Divisia quantity index \(\sum \nolimits _{j}w_jdlogx_j\).
see Revenue Commissioners (2010).
For clarity, we present only the results based on a value of \(e=1\). As before, higher values of \(e\) will place more relative weight on distributional concerns.
See Appendix for actual rankings of goods by \(MRC\).
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Acknowledgments
I would like to thank David Madden for countless helpful comments on this paper. I also thank Tim Callan, participants at the ISNE 2013 Conference at NUIM, participants at the ESRI seminar series, Robert Chirinko and two anonymous referees for comments. I am grateful to the ESRI for funding. I thank the Irish Social Science Data Archive (ISSDA) for providing access to the HBS data. All remaining errors are my own.
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Appendices
Appendices
1.1 Appendix A: Derivation of marginal revenue cost expression
The production side of the model is straightforward. Assuming fixed producer prices and constant returns to scale, we have:
where \(q\) is the vector of consumer prices, \(p\) is the fixed vector of producer prices, and \(t\) is a vector of specific taxes. Given the simplifying assumptions about the production side of the economy, Eq. 20 shows that any tax increases will be fully reflected in consumer prices.Footnote 32
With consumer prices \(q\), the demand of household \(h, x^{h}(q)\), maximises utility \(u_{h}(x^{h})\), subject to the household budget constraint. The indirect utility function, \(v^{h}(q)\), then gives the maximum utility possible at prices \(q\). Assuming incomes are fixed, we have a Bergson–Samuelson social welfare function which can be written as a function of prices:
We have aggregate demand vector \(X(q)\) given by:
and government tax revenue given by:
Then, from Eq. 23 we have:
By Roy’s identity, we have:
where \(\alpha ^{h}\) is the private marginal utility of income. We can then say that:
where \(\beta ^{h}=\alpha ^{h}\frac{\partial {W}}{\partial {u}^{h}}\) is the social marginal utility of income, or the welfare weight of household \(h\).
In the original Ahmad and Stern methodology, tax reform recommendations were made using the \(MSC\) rather than \(MRC\) of taxation of a good, where the \(MSC\) is defined as:
From Eqs. 26 and 24, we can estimate the \(MSC\) of a euro raised through a change in the indirect tax on good i by:
In order to deal with issues in this methodology caused by commodity-specific Laffer effects, where \(\frac{\partial {R}}{\partial {t}_{i}}<0\) resulting in difficulties ranking \(MSCs\), Madden (1995a) recommends using the marginal revenue cost (\(MRC\)). \(MRC_{i}={1}/{MSC_{i}}\) is simply the inverse of Eq. 28. With some rearranging:
which is the expression in the paper.
Note that the same expression can be used to estimate the \(MRCs\) in the case of proportional taxes(\(t^p\)), rather than specific taxes (\(t\)). With proportional taxes, we have:
Government tax revenue then becomes:
The expression for the \(MRC\) can then be written as:
Letting the \(p_i\)s cancel, and multiplying above and below by \(q_i\), we have:
which, again, is the same expression as used in the paper. Madden (1995b) specifies the Ahmad and Stern tax reform model using proportional taxes when extending the model to include labour supply. He found that the ranking of \(MRCs\) in Ireland showed little sensitivity to the inclusion of labour supply.
1.2 Appendix B: Summary statistics
The graph below shows how the price of each good varies across the sample period. Most price variation occurs between years rather than within years (Fig. 2).
Table 9 shows the budget share of each good in each year of the analysis. Between 1987 and 2005, services and other goods increased its budget share by over 12 percentage points. The budget share of the other five goods decreased over the same time period. In 2009/2010, however, which was during a deep recession in Ireland, this trend is reversed. The share of services and other goods decreases for the first time in the sample period, while the share of food, tobacco, clothing and transport and fuel increases. The share of alcohol continues to decline. The pattern of budget shares for food is reflective of Engel’s law. The budget share for food was decreasing as average incomes were rising in Ireland. The trend was reversed in the 2009/2010, however, when Ireland was in deep recession.
In Sect. 2.3.2, we highlighted the importance of taking account of observed zero-expenditures when estimating elasticities. Table 10 shows this issue is prevalent in three of the six goods used in the analysis. There are also negligible levels of observed zero-expenditures for food and transport and fuel. However, these are less than half a percentage of total observations in each case, so we do not apply the ZA- correction for these goods. As mentioned above, we use Shonkwiler and Yen’s approach to account for the zero-expenditures in the data.
1.3 Appendix C: MRC rankings
1987 | 1999 | 2009 | ||||||||||||||||
---|---|---|---|---|---|---|---|---|---|---|---|---|---|---|---|---|---|---|
AIDS | QUAIDS | AIDS | QUAIDS | AIDS | QUAIDS | |||||||||||||
NA | PS | ZA | NA | PS | ZA | NA | PS | ZA | NA | PS | ZA | NA | PS | ZA | NA | PS | ZA | |
\(e=0\) | ||||||||||||||||||
Food | 5 | 6 | 3 | 4 | 5 | 3 | 4 | 6 | 1 | 4 | 5 | 1 | 4 | 6 | 1 | 4 | 5 | 1 |
Alcohol | 2 | 1 | 1 | 2 | 2 | 1 | 2 | 2 | 2 | 2 | 2 | 3 | 2 | 2 | 3 | 2 | 2 | 3 |
Tobacco | 1 | 2 | 6 | 1 | 1 | 6 | 1 | 1 | 6 | 1 | 1 | 6 | 1 | 1 | 6 | 1 | 1 | 6 |
Clothing | 4 | 4 | 5 | 5 | 4 | 5 | 5 | 4 | 5 | 5 | 4 | 4 | 5 | 4 | 4 | 5 | 4 | 4 |
T&F | 3 | 3 | 4 | 3 | 3 | 4 | 3 | 3 | 3 | 3 | 3 | 2 | 3 | 3 | 2 | 3 | 3 | 2 |
Serv&Oth | 6 | 5 | 2 | 6 | 6 | 2 | 6 | 5 | 4 | 6 | 6 | 5 | 6 | 5 | 5 | 6 | 6 | 5 |
\(e=1\) | ||||||||||||||||||
Food | 3 | 5 | 2 | 3 | 5 | 2 | 3 | 5 | 1 | 3 | 5 | 1 | 3 | 5 | 1 | 3 | 5 | 1 |
Alcohol | 2 | 1 | 1 | 2 | 2 | 1 | 2 | 2 | 2 | 2 | 2 | 3 | 2 | 2 | 3 | 2 | 2 | 3 |
Tobacco | 1 | 2 | 5 | 1 | 1 | 5 | 1 | 1 | 6 | 1 | 1 | 6 | 1 | 1 | 6 | 1 | 1 | 6 |
Clothing | 5 | 4 | 6 | 5 | 4 | 6 | 5 | 4 | 4 | 5 | 4 | 4 | 5 | 4 | 4 | 5 | 4 | 4 |
T&F | 4 | 3 | 4 | 4 | 3 | 4 | 4 | 3 | 3 | 4 | 3 | 2 | 4 | 3 | 2 | 4 | 3 | 2 |
Serv&Oth | 6 | 6 | 3 | 6 | 6 | 3 | 6 | 6 | 5 | 6 | 6 | 5 | 6 | 6 | 5 | 6 | 6 | 5 |
\(e=2\) | ||||||||||||||||||
Food | 3 | 5 | 2 | 3 | 4 | 2 | 3 | 5 | 1 | 2 | 3 | 1 | 3 | 5 | 1 | 3 | 4 | 1 |
Alcohol | 2 | 1 | 1 | 2 | 2 | 1 | 2 | 2 | 3 | 3 | 2 | 3 | 2 | 2 | 3 | 2 | 2 | 3 |
Tobacco | 1 | 2 | 5 | 1 | 1 | 4 | 1 | 1 | 6 | 1 | 1 | 6 | 1 | 1 | 6 | 1 | 1 | 6 |
Clothing | 5 | 4 | 6 | 5 | 5 | 6 | 5 | 4 | 5 | 5 | 5 | 4 | 5 | 4 | 4 | 5 | 5 | 4 |
T&F | 4 | 3 | 4 | 4 | 3 | 5 | 4 | 3 | 2 | 4 | 4 | 2 | 4 | 3 | 2 | 4 | 3 | 2 |
Serv&Oth | 6 | 6 | 3 | 6 | 6 | 3 | 6 | 6 | 4 | 6 | 6 | 5 | 6 | 6 | 5 | 6 | 6 | 5 |
\(e=5\) | ||||||||||||||||||
Food | 2 | 4 | 1 | 2 | 2 | 1 | 2 | 4 | 1 | 2 | 2 | 1 | 2 | 4 | 1 | 2 | 3 | 1 |
Alcohol | 3 | 1 | 2 | 3 | 3 | 2 | 4 | 2 | 4 | 4 | 4 | 4 | 4 | 2 | 6 | 4 | 5 | 6 |
Tobacco | 1 | 2 | 3 | 1 | 1 | 3 | 1 | 1 | 3 | 1 | 1 | 3 | 1 | 1 | 4 | 1 | 1 | 4 |
Clothing | 5 | 5 | 6 | 5 | 5 | 6 | 6 | 5 | 6 | 6 | 6 | 6 | 5 | 5 | 5 | 5 | 4 | 5 |
T&F | 4 | 3 | 5 | 4 | 4 | 5 | 3 | 3 | 2 | 3 | 3 | 2 | 3 | 3 | 2 | 3 | 2 | 2 |
Serv&Oth | 6 | 6 | 4 | 6 | 6 | 4 | 5 | 6 | 5 | 5 | 5 | 5 | 6 | 6 | 3 | 6 | 6 | 3 |
Merit MRCs (\(e=1\)) | ||||||||||||||||||
Food | 4 | 5 | 3 | 4 | 4 | 5 | 3 | 5 | 1 | 2 | 4 | 1 | 5 | 5 | 1 | 3 | 4 | 1 |
Alcohol | 1 | 1 | 1 | 1 | 1 | 2 | 1 | 2 | 2 | 1 | 2 | 2 | 2 | 2 | 2 | 1 | 3 | 3 |
Tobacco | 5 | 4 | 6 | 5 | 5 | 1 | 5 | 4 | 6 | 5 | 5 | 6 | 6 | 4 | 6 | 5 | 5 | 6 |
Clothing | 3 | 2 | 4 | 3 | 3 | 6 | 2 | 1 | 4 | 3 | 1 | 4 | 3 | 1 | 5 | 4 | 1 | 5 |
T&F | 2 | 3 | 2 | 2 | 2 | 3 | 4 | 3 | 3 | 4 | 3 | 3 | 1 | 3 | 3 | 2 | 2 | 2 |
Serv&Oth | 6 | 6 | 5 | 6 | 6 | 4 | 6 | 6 | 5 | 6 | 6 | 5 | 4 | 6 | 4 | 6 | 6 | 4 |
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Savage, M. Indirect tax reform and the specification of demand: the case of Ireland. Int Tax Public Finance 23, 368–399 (2016). https://doi.org/10.1007/s10797-015-9362-3
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DOI: https://doi.org/10.1007/s10797-015-9362-3