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Experimental cost-of-living indexes: a summary of current research.

Mary F. Kokoski is an economist in the Office of Prices and Living Conditions, Bureau of Labor Statistics.

Experimental cost-of-living indexes: a summary of current research

Mary F. Kokoski

The Consumer Price Index (CPI) is "a measure of the average change in prices paid by urban consumers for a fixed market basket of goods and services."1 As a policy tool, it is used to assess changes in households' cost of living and to adjust income or other compensatory payments to households, including wages, salaries, and pensions (private, military, civil service, and Social Security). Since 1985, the schedule of Federal income tax brackets, exemptions, and deductions has been indexed to the CPI.

Over time, the Bureau of Labor Statistics has implemented changes that improve the quality and relevance of the CPI as a measure of changes in the cost of consumption for the average household. In 1978, the sample of consumers surveyed to develop the CPI was broadened to permit the computation of an index, the CPI-U, that would represent the entire urban population (about 80 percent of the noninstitutional U. S . population), rather than only wage earners and clerical workers as did the earlier index, still published as the CPI-W. At that time, the statistical methodology was also improved, employing a scientific probability basis to provide a more representative sample of goods and services consumed. Beginning in 1983, a rental equivalence approach was adopted in the cpi-u so that the index would measure the consumption of housing services and not the investment component of homeownership. Beginning in 1987, the CPI was rebased to reflect the expenditure pattems of households as determined by the Bureau's 1982-84 Consumer Expenditure Survey,2 which replaced those derived from the 1972-73 expenditure survey, and new commodities (such as personal computers) have been added to the market basket. Refinement of sampling and pricing methodologies is, and will continue to be, an ongoing process.

Even if it were technically flawless, the CPI would not be ale only possible measure of price change and is not intended to address all issues concerning the welfare effects of price changes. No single index measure could do so. Because it is a fixedweight Laspeyres index.(3) the CPI cannot incorporate in timely fashion the effects of changes in the consumption pattems of households due to relative price changes-that is, it does not capture the substitution behavior of consumer households between rebasing periods. Also, it represents the average price changes affecting consumer units, not the price changes affecting any one household or group of consumers. As a consumption-based index, it excludes the effects of price changes on income tax liabilities, as well as the welfare effects of changes in nonconsumption items (such as environmental amenities or investment values). To meet these concems, a plethora of measures of price change could be defined: indexes with several sets of expenditure weights, different indexes for various types of households, and indexes that incorporate other variables affecting household welfare. For a specific analytical or policy purpose, it is possible that one of these types of indexes would provide a better measure than the CPI.

The advantages of the CPI are that it represents a clearly defined measurement concept and is constructed on the basis of a well-defined sample of expenditures and prices. As a Laspeyres price index of consumption, its properties with respect to other theoretical indexes of welfare change are well understood.(4) Thus, it is not likely to be replaced by another type of measure in the near future. Other index measures, however, may serve as complements to the CPI in addressing various issues. These alternatives also may provide insights into the character of, and suggest improvements to, the CPI itself.

Three types of new indexes-multiweighted indexes, demographic groupspecific indexes, and a price index including income taxes-are currently being analyzed at the research level, using die resources of die 1972-73 and continuing (1980 forward) Consumer Expenditure Surveys. Although preliminary in nature, the results for these altemative index measures supplement past research at die Bureau and suggest the potential usefulness of these indexes for several of the applications that require a price index measure. These results are summarized below.(5)

A multiweighted index

A frequently voiced criticism of the fixedweight CPI is that it inherits a substitution bias; that is, it ignores changes in expendiwres made by consumers in response to changes in relative prices. If, for example, the price of beef rises more rapidly than that of poultry, then consumers may substitute poultry for the relatively more expensive beef. Because of this change in consumption pattems, the actual average price change for households would be less than that indicated by an index with expenditure shares fixed at the base-period pattern. The difference between the fixedweight index and a "true" index, which incorporates substitution behavior, is the substitution bias. Over time, as the cumulative changes in relative prices increase, substitution bias also will increase.

To minimize substitution bias, expendiwre weights can be updated periodically or an index with multiple expenditure weights (a "multiweighted index") can be constructed. For the CPI, expenditure weights are updated about once per decade, the most recent revision having occuffed in January 1987. Because the Consumer Expendiwre Survey has been conducted on a continuing basis since 1980, it is now possible to update expenditure weights more frequently and to produce multiweighted indexes. Several sets of expenditure weights can be used to produce chainweighted indexes, already in use as official series published by other nations (such as the United Kingdom(6)). In the Laspeyres form, these indexes include expenditure information from a series of past (but not the current) periods. The reference expenditure weights are systematically moved forward over time, thus reducing the potential for substitution bias .(7) "Superlative" indexes,(8) which may be either chained or fixed-base, use expenditure weights from both past and current periods. Under a given set of assumptions, superlative indexes, such as the Fisher and Tornqvist forms,(9) represent "true" cost-of-living indexes, and thus may provide a feasible (and fairly general(10) measure of the substitution bias inherent in the fixed-weight Laspeyres index.

In mathematical teffns, the fixed-weight Laspeyres price index is:

(1) L.sub.t,r = N(over)[sigma](over)i=1 Pit qir / N(over)[sigma](over)i=1 Pir qir

where pi, is the price of good i in period t; qit is the quantity of good i consumed in period t; r is the reference period for the consumption vector q (= qir, q2r, . . . , qNr); and L.sub.t,r is the Laspeyres price index for period t compared to period r. The expenditures Pir qir (i = 1, . . . , N) that compose the reference-period market basket are the result of household consumption decisions made in period r at the prevailing set of prices Pr (= Plr , . . . , PNr). The index in equation (1) compares the cost of purchasing the market basket q, under die new prices p, and the reference-period prices Pr; it ignores the possibility that consumers are likely to change their expenditure pattems by purchasing a new market basket q, at the new prices pt. If, for example, the price of good i rises rapidly and die price of good j remains the same, then it is likely that qit, < qir and qjt > qjr (unless i and j are complementary goods). By maintaining the reference expenditures qir and qjr, the Laspeyres index provides an upper bound to the effects of the price changes on consumer welfare." This discrepancy is the source of substitution bias and, as previously noted, it is likely to increase over time as differences in relative prices increase.(12)

A chained Laspeyres index is constructed by multiplyin"chaining," a series of period-to-pefiod Laspeyres indexes, and is given by:

(2) L.sup.c.sub.t,r = L.sub.r,r+1 .sup.. L.sub.r+1,r+2.sup.. . . . L.sub.t-1,t

([sigma]iPi,r+lqi,r / [sigma]iPi,rqi,r) . ([sigma]iPi,r+2qi,r+1 / [sigma]pi,r+1qi,r+1) . . .

. ([sigma]iPi,tqi,t-1 / [sigma]iPi,t-1qi,t-1)

where L.sup.c.sub.t,r is the chained Laspeyres index for reference period r and comparison period t. As equation (2) shows, the reference period for each component index is its previous period, so that the index includes the expenditure weights from periods r, r + 1, r + 2, . . . t - 1, not just the earliest period r. Because the divergence in relative prices, and thus expendiwre patterns, is likely to be smaller between two adjacent periods than between period r and any comparison period r+2, . . . , t, the chained index would be expected to inherit less substitution bias than the fixed-weight index in equation (1).(13)

In both the fixed-base and the chainweight contexts, die Fisher's ideal index and the Tomqvist index may be constructed. These superlative indexes in effect represent die geometric means of two price indexes, one based on period r as the reference level of consumer welfare and one based on die period t level of welfare as die reference. Because of the way in which they incorporate more than one expenditure pattern, the superlative indexes are themselves true cost-of-living indexes under certain rather flexible assumptions about consumer preferences.

The fixed-base (T.sub.t,r) and chain-weighted (T.sup.c.sub.t,r) Tomqvist indexes are given by (3a) and (3b) , respectively:

(3a) T.sub.t,r [is identical with] N over II over i=1 (pit/pir)( + , and

(3b) T.sup.c.sub.t,r [is identical with] t over II over tau =r+1 T.sub.tau,tau-1

where = pir qir/[Sigma]Pir qir and + P it qit / [Sigma]Pit qit . The fixed-base (F.sub.t,r) and chain-weighted (f.sup,c.sub.t,r) Fisher's ideal indexes are given by:

(4a) F.sub.t,r [is identical to] ([sigma]i Pit qir / [sigma]i Pir qir) 1 / 2 . ([sigma]i Pit qit / [sigma] Pir qit) 1 / 2 , and

(4b) F.sup.c.sub.t,r [is identical to] t over II over tau=r+1 F.sub.tau,tau-1

Unlike their Laspeyres counterparts in equations (1) and (2) , the superlative index forms require expenditure data for both past periods and the current period t. This limits their usefulness as up-to-date official series because data on consumer expenditures require time for collection and processing. However, these indexes can serve as a benchmark for assessing the magnitude of the substitution bias inherent in the Laspeyres indexes for recent past periods. By comparing (1) to (3a), (3b), (4a), or (4b) , the degree of bias in the Laspeyres form can be tracked over time.(14)

In a preliminary investigation of these issues, expenditure data from the 1982-84 Consumer Expendiwre Surveys were aggregated by calendar quarter for 160 categories of expenditures." These expendiwre categories correspond closely to those used to construct the CPI. From these data, both quarterly and annual average indexes were constructed. The calculated fixedbase ("direct") and chained indexes are presented in table 1. The reference period for the quarterly indexes is first-quarter 1982, while that for the annual indexes is 1982.

The substitution bias may be measured in percentage terms using the equation:

(5) Bias l = ( L - s over s - 100) . 100

where S represents the "true" or, in this case, superlative index. 16 Alternatively, it may be measured in terms of the cumulative difference in price change from the reference period:

(6) Bias 2 = L -S

or in teffns of die period-to-period difference in measured price change:

(7) Bias 3 = ( L.sub.t over L.sub.t-1 - S.sub.t over S.sub.t-1) . 100

To measure the substitution bias over the 1982-84 period, the difference between the direct Laspeyres index and the coffesponding Tomqvist (T) and chained Tomqvist (TO) indexes are calculated using each of die above measures. The results are provided in table 2. Analogous measures using the Fisher index also may be constructed, but are not presented here because the values of the two superlative indexes are very close.17

The quarterly indexes indicate an increase of about 11 percent in the cost of living from first-quarter 1982 to fourthquarter 1984, while the annual average change from 1982 to 1984 is about 7 percent. Generally, the fixed-base Laspeyres index increased more quickly than the chained Laspeyres index, a result consistent with substitution among goods in response to price changes (although by no means a proof of such behavior). The correspondence between the fixed-base and chained superlative indexes is somewhat closer than for the Laspeyres forrn, although it is not exact to one decimal place except for the annual indexes. Some of this discrepancy may be attributed to large differences between p, and p, or between P[tau]-1 and P.sub.tau,(18) or to differences in preferences across periods.(19) Measurement error may play a significant role, and the variance of quarterly expenditure surveyderived cost weights may be high.

This means that the measures of substiwtion bias in table 2 differ somewhat when based on T or T.sup.c. The measure Bias 1 ranges from 3 to 11 percent across the quarterly series and from 1.4 to 3 percent for the annual series. Bias 2, a cumulative measure, indicates that the absolute divergence between L and the superlative measure generally increases over time. The periodto-period Bias 3 ranges from 0.1 to 0. 3 percent. It is generally higher for comparisons to T, although the significance of this result is suspect.

According to the economic index number literature, multiweighted indexes, which are now feasible because of the continuous collection of Consumer Expenditure Survey data, may inherit less substiwtion bias than the fixed-weight Laspeyres index. In this analysis, multiweighted indexes have been used to assess the magnitude of substitution bias in fixed-weight indexes such as the CPI. Further research is under way to explore altemative methods of producing multiweighted indexes, particularly to better exploit the panel structure of the expenditure survey data and to examine the effects of seasonal (or other systematic) variations in relative prices and expenditures in the quarterly context.(20)

Indexes for demographic groups

Although used for a variety of policy purposes, the CPI-U represents the effects of price changes on an average or "representative" household. To the extent that a given household's expenditure pattems differ from the population average, the effects of relative price changes on this household will not be reflected by the CPI value. For example, families with a relatively large share of their consumer expenditure devoted to food will experience a greater increase in their cost of living than will households with a small expenditure share for food when food price increases are relatively large. Similarly, an elderly household may be more greatly affected by changes in prices of household fuels and medical care than by changes in prices of furniture and entertainment commodities.

If it is assumed that die expenditure pattems of households are related to the households' demographic attributes, then a price index for a demographic subgroup might, on average, be more representative of die price changes experienced by a household in that subgroup than would the CPI for all households. Production of a reliable set of subgroup price indexes requires information on the relationship between demographic attributes and expenditures by households, as well as the variance of consumption pattems within and between the population subgroups.

Analysis of the variation in price indexes across households has been done by Robert Michael and Robert Hagemann. (21) In Hagemann's study, data from the interview portion of the 1972-73 Consumer Expendiwre Survey were used to perform regressions of demographic attributes on householdspecific price indexes. His results indicate that, while some demographic attributes had a statistically significant influence on expenditure pattems, variability in expenditure patterns within subgroups was still at least as large as that across groups. To assess the importance of this result for producing subgroup indexes for moreaggregate demographic groups, experimental subgroup indexes for 1972 expenditure survey households have now been constructed. 22 Subgroup mean expenditure shares (rather than household-specific indexes) were used to construct the subgroup indexes, which were limited to households that rented their dwellings. Age (64 and under, over 64) of reference person, 23 household composition (singles, couples, families, single parents), and retirement status (of reference person) provided the demographic group disaggregation for the 1972 sample of renter households. (24) The indexes were based on 54 categories of goods and services.

The demographic group indexes and 1972 sample sizes are presented in table 3. The results show that, over the 8-year period, the Laspeyres indexes may diverge by as much as 4 index points across demographic subgroups. In addition, the indexes are higher for larger households (for example, families and couples versus singles).

In table 4, each of the demographicgroup Laspeyres index values is compared to the index value for all renters, and also to the index for the general age and household composition classifications to which the group belongs. For example, the index for families with householders under age 64 is compared to the indexes for: all renters (column 1); all households with reference persons under age 64 (column 2); and all families (column 3). The results show that, in most cases, age subgroup indexes do not come closer to the demographic group indexes (and may even differ more from diem) than does the all-renters index. Even for the over-64 group, the sample from which expenditure shares for a CPI for retired persons might be obtained, an over-64 subgroup index provides a poorer approximation of the index for over-64 singles than does the all-renters index. Likewise, an index for all retirees does not necessarily well represent the retired singles. For the under64 households subgroup, however, indexes based upon household composition perform relatively well.

Overall, it appears that variations in expendiwre patterns within broadly defined demographic groups may cause demographic subgroup indexes to be less representative of the households within the subgroup than would an aggregate price index . In this analysis, indexes based upon household composition may hold some measure of promise, but further research will be needed to explore this area more fully. An even more important need is to assess the variance of these indexes and comparative measures. With the availability of expendiwre survey data for 1980-85, a more detailed and rigorous analysis of the relationship between household attributes and expenditure is possible. Larger sample sizes may permit greater disaggregation of the population into more specific demographic groups, as well as a greater disaggregation of the commodity and service categories. In addition, the importance of the period(s) chosen for analysis should be investigated.

The tax and price index

The CPI measures the change in total expenditure needed to enable the consumer to purchase a fixed market basket of commodities and services under a new set of prices. In many cases, however, it is used to adjust components of income (such as wages and pensions), and not household expenditures, as the prices of expenditure goods change. Thus, it can be argued that an "income-based" cost-of-living measure(25) would be more appropriate than an "expenditure-based" measure such as the CPI. An income-based cost-of-living (ICOL) index would assess the changes in pretax income needed by consumers to enable them to achieve the same level of consumption as before the price changes. Under a progressive tax system, it is expected that index computation in terms of pretax income will differ from that in terms of consumption expenditures because a larger share of the consumer's income must be devoted to tax payments as income increases. Such an income-based index would also reflect changes in tax rates and the structure of the tax system as these variables affect the difference between pre-tax and disposable income.(26)

Robert Gillingham and John Greenlees have constructed a fixed-weight pretax income index, the tax and price index (TPI), to capture die impact of Federal and State income taxes on the welfare effects of price changes." It includes a market basket of consumer goods and services and (unlike the CPI) also incorporates real savings, 28 charitable contributions, and nonconsumpfion goods (such as professional memberships and consumer financial services) in the set of expenditures for households.(29) This set of expenditures was determined for each household in the 1972-73 expendiwre survey sample as its reference expenditure pattem. Future consumption, public goods, and environmental variables were not explicitly included, nor was income from sources other than wages and salaries and self-employment.

For each household in the sample, information was gathered to determine its Federal and State and local income tax burden for any given level of household income. This information includes tenure staws (homeowners versus renters), filing staws (it was assumed, for lack of data, that all married couples filed jointly), State and county of residence, family composition (for example, number of dependents), deductible expendiwres (such as charitable contributions and sales taxes paid), and so forth. The State Tax Handbook and State Tax Guide, 30 Your Federal Income Tax, (31) and copies of the 1040 and 1040A forms(32) provided the specific tax rules, brackets, and rates to be applied. The computation of the TPI then involved solution of the following problem: "given a [reference] value of consumption expenditures M.sub.x, what is the value of gross [pretax] income Y such that after-tax income equals M.sub.x ?"(33)

In general terms, the TPI is given by:

(8) TPI.sub.t,r [is identical to] (N [Sigma] i=1 Pit qir + T.sub.t) / (N [Sigma] = 1 Pir qir + T.sub.r)

[is identical to] (n [Sigma] i = 1 Pit qir + tau(P.sub.t, t.sub.t; q.sub.r, Z,sub.r, S.sub.r) / N [Sigma] i=1 Pir qir + tau(P.sub.r, t.sub.r; q.sub.r, Z.sub.r, S.sub.r)) where, for reference period r and comparison period t: pi is the price of consumption good i; qi is die quantity of good i consumed; and Tis the tax burden, which is a function, T, of prices (p), tax parameters (t), consumption (q), expenditure on nonconsumption goods (z), and the demographic attributes that determine tax filing status and liabilities (S). Because tax liabilities vary by household, the TPI Was constructed at the household level for each of the 7,242 expenditure survey households in the sample and averaged to derive an aggregate index. An expenditure-based price index, analogous to the CPI, was derived for this sample as well for comparison with the TPI. (34)

The resulting TPI, "CPI," and indexes of changes in the various income tax components are given in table 5, where the reference expenditures Prqr are for 1972-73. The percentage changes in these indexes are also shown.

The results show that all tax components and the TPI have risen more quickly than the prices of market commodities. In 1985, the TPI exceeded the "CPI" by 36.7 index points. Thus, even if pretax incomes were indexed by the "CPI," the households would, on average, still have experienced a loss in after-tax purchasing power. The percentage changes in the indexes show that the tax components and the TPI were generally increasing more quickly than prices up through 1981. The "bracket creep" effect appears to have caused much of the divergence between the annual average rates of increase in the TPI and the "CPI." Changes in tax system parameters also influenced the TPI series: the tax surcharge in 196869; the Personal Exemption Credit and Earned Income Credit in 1975; the Credit for the Elderly and the Taxable Income Credit in 1976, which reduced the rise in taxes; the lower marginal rate schedules in 1979; and the Economic Recovery Tax Act of 1981, which reduced the rate of increase in the TPI in 1982-85. Despite the increasing rates for the State tax and FICA components, the TPI increased more slowly than the "CPI" during 1981-84. In 1985, die first year in which Federal income tax brackets were indexed by the Consumer Price Index, the increase in the TPI was only 0.2 index points greater than the increase in the "CPI."

The TPI provides a complement to the published CPI which may be used to address such issues as the effect of indexing Federal tax brackets by the CPI; the effect of differential tax treatment of population subgroups (homeowners, retirees, and so forth); and the net effect of substituting indirect (such as sales) for direct (income) taxes. If, for example, a value-added or sales tax were implemented to replace some or all of the revenues generated by the income tax, the TPI would reflect both die increase in the prices of goods and the reduction in income tax burdens; the CPI (which incorporates sales taxes) would capwre only the sudden increase in retail prices. However, neither index, as now constructed, would capture changes in other taxes, such as those on unearned (asset) income, or the effects of tax changes on the consumption of leisure. Improvements to the tax and price index may be made, such as the inclusion of direct taxes on asset income and the incorporation of greater detail in the expenditure categories and demographic attributes. Consideration of the labor-leisure choice in this framework is also an interesting possibility.

RESEARCH IS UNDER WAY to expand upon the results of this report and to possibly produce similar experimental indexes on a production basis. The availability of data from the continuing Consumer Expendiwre Survey provides a basis for improving upon this preliminary analysis. Production versions of these indexes would thus be comparable to the revised CPI, which has expenditure weights based on 1982-84 household consumption data.


ACKNOWLEDGMENT: The author thanks Kimberly Zieschang, John Early, and other colleagues who provided helpful comments on earlier versions of this report.

1 BLS Handbook of Methods, Volume II: The Consumer Price Index, Bulletin 2134-2 (Bureau of Labor Statistics, April 1984).

2 The Consumer Expendiwre Survey, conducted by the Bureau of the Census for the Bureau of Labor Statistics, provides detailed information on the expendiwres and demographic attributes of a representative sample of U.S. households. It consists of two distinct components-the Interview Survey, which collects information from a rotating panel of households for five consecutive calendar quarters each; and the Diary Survey, which consists of two weekly diaries of specific expenditures recorded by each participating household. The Interview component is designed to capture large and/or infrequent household expenditures (such as major appliances) and the Diary component is designed to collect information on smaller, more frequent types of expendiwres (as for food items).

3 It is actually a modified Laspeyres index, although the expenditure weights are fixed for a reference pefiod.

4 Robert Pollak, "The Treatment of Taxes in the Consumer Price Index, " in W. Erwin Diewert and Claude Montmarquette, eds. , Price Level Measurement (Ottawa, Statistics Canada, 1983); and Robert Gillingham, "A Conceptual Framework for the Consumer Price Index," in Proceedings, Business and Economic Statistics Section (American Statistical Association, 1974), pp. 254-65.

5 A detailed and more technical discussion is available in Mary F. Kokoski"A Report on Experimental Indices of the Cost of Living," Report no. 751 (Bureau of Labor Statistics, 1987); and Robert Gillingham and John Greenlees, "The Impact of Direct Taxes in the Cost of Living," Journal of Political Economy, Vol. 95, 1987, pp. 775-96.

6 R. F. Fowler, "Some Problems of Index Number Construction," Studies in Official Statistics Research Series No. 3 (London, Department of Employment and Productivity, 1970).

7 Household expenditure pattems may change over time independently of changes in relative prices. By including continuous updates of expendiwre information, the multiweighted index also accommodates the changes in consumer preferences due to shifting tastes, lifestyles, and so forth.

8 W. Erwin Diewert, "Exact and Superlative Index Numbers," Journal of Econometrics , Vol. 4, 1976, pp. 115-45.

9 W. Erwin Diewert, "The Theory of the Costof-Living Index and the Measurement of Welfare Change," in W. Erwin Diewert and Claude Montmarquette, eds., Price Level Measurement (Ottawa, Statistics Canada, 1983), pp. 163-223.

10 The alternative, parametric approach to constructing true cost-of-living indexes requires econometric estimation of consumer demand relationships. The resulting "parametric" true costof-living indexes are then dependent upon the assumptions and functional form chosen for the consumer demand model.

11 A theoretical derivation and proof of this assertion are available in Di"Exact and Superlative Index Numbers."

12 Steven Braithwait, "The Substitution Bias of the Laspeyres Price Index: An Analysis Using Estimated Cost-of-Living Indexes," American Economic Review, Vol 70, 1980, pp. 64-77.

13 Some concern has been expressed in the context of chained indexes about the problem of "chain drift." In the most general sense, drift may occur if approximation or measurement errors in the period-to-period indexes cumulate as these indexes are multiplied together to construct the chain. Specific characterizations of "drift" have not been fully resolved in the literature as yet. See Bohdan J. Szulc, "Linking Index Number Series," in W. Erwin Diewert and Claude Montmarquette, eds., Price Level Measurement (Ottawa, Statistics Canada, 1983); and F. G. Forsyth and R. F. Fowler, "The Theory and Practice of Chain Price Index Numbers," Journal of the Royal Statistical Society, Vol. 144, 1981, Part 2, pp. 224 16.

14 Marilyn Manser and Richard McDonald, "An Analysis of Substitution Bias in Inflation Measurement, 1959-82," Econometrica, Vol. 56, 1988, pp. 909-30.

15 The data base included reports from both the Diary and Interview portions of the survey.

16 p. J. Lloyd, "Substitution Effects and Biases in Nontrue Indices," American Economic Review, Vol. 65, 1975, pp. 301-13.

17 See Manser and McDonald, "An Analysis."

18 Recall that the superlative indexes represent the geometric means of two price indexes with different reference periods. The values of these implicit component indexes may differ because a different set of reference expenditures serves as the basis for the comparison of indexes.

19 Consumers may require more than 3 months to accommodate price changes by adjusting their expendiwres, and may also exhibit seasonal pattems in their consumption behavior.

20 Seasonal or other cyclical pattems in prices and expendiwres can, in principle, cause the chained index and the direct index to diverge, or "drift."

21 Robert Michael, "Variation Across Households in die Rate of Inflation," Journal of Money, Credit, and Banking, Vol. 11, 197 9, pp. 32-46; and Robert Hagemann, "The Variability of Inflation Rates Across Household Types," Journal of Money, Credit, and Banking, Vol. 14, 1982, pp. 494-510.

22 These research indexes were created by using the average expendiwre patterns of the given demographic groups as cost weights for the national CPI price series of each individual commodity category. It is possible that these population subgroups may have different geographic distributions, purchase different varieties of goods, shop in different outlets, or pay different prices (an example being senior citizen discounts). Such effects will not be reflected in the indexes presented here. (See Commissioner of Labor Statistics Janet L. Norwood, Statement before the Special Committee on Aging, U.S. Senate, June 29, 1987.)

23 In the Consumer Expenditure Survey, the reference person is the first member of the consumer unit that the survey respondent mentions as an owner or renter of the household premises during the initial interview.

24 Data are from the Interview portion of the expendiwre survey only.

Preliminary comparisons of these results to those for a 1980 sample (comparable for renters only) has been done, but sample sizes in the latter survey are too small to permit discussion here.

25 Robert Pollack, "The Treatment of Taxes in the Consumer Price Index," unpublished paper (Bureau of Labor Statistics, 1972).

26 It is implicitly assumed that income tax payments and govemment benefits supplied from these revenues are not correlated. Government services (such as defense) are not included in the consumers' market basket of goods and services. (For a discussion of indexes that incorporate such public goods, see Steven A. Cobb, "Interarea Cost of Living Measurement with Nonmarket Goods: A Demand Systems Approach," Working Paper No. 140 (Bureau of Labor Statistics, 1983).) FICA taxes are treated likewise, because the link between the payment of these taxes and future Social Security benefits is somewhat tenuous.

27 See Gillingham and Greenlees "The Impact."

28 This is monetary savings divided by a price index.

29 These expendiwres have investment components, that is, they yield benefits in future periods but are purchased in the current period. Such expenditures are inappropriate in an expenditure-based index such as the CPI (see Gillingham "A Conceptual Framework"), but are affected by the tax code.

30 Commerce Clearing House, Inc. State Tax Handbook, various annual issues; and Commerce Clearing House, Inc., State Tax Guide, various issues.

31 U.S. Internal Revenue Service, Your Federal Income Tax, Publication 17, various annual issues.

32 U.S. Internal Revenue Service, Individual Income Tax Retums, Forms 1040 and 1040A, various annual issues.

33 Gillingham and Greenlees, "The Impact."

34 The indexes here were based on a disaggregation of consumption expendiwres into 37 categories of goods and services.

Both the TPI and "CPI" in this analysis employ the equivalent rent measure for homeownership. This rental equivalence approach has been adopted by the official CPI under the 1987 revision.
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Author:Kokoski, Mary F.
Publication:Monthly Labor Review
Date:Jul 1, 1989
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