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One-digit industry wage structure in British Household Panel Survey data (Waves One to Eleven; N = 63 000). Average sample wage = £1163 per month (in real.

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Presentation on theme: "One-digit industry wage structure in British Household Panel Survey data (Waves One to Eleven; N = 63 000). Average sample wage = £1163 per month (in real."— Presentation transcript:

1 One-digit industry wage structure in British Household Panel Survey data (Waves One to Eleven; N = 63 000). Average sample wage = £1163 per month (in real 1996 Pounds).

2 Standard Industrial Classification Divisions: 0 Agriculture, forestry & fishing (£902) 1Energy & water supplies (£1758) 2Extraction of minerals & ores other than fuels; manufacture of metals, mineral products & chemicals (£1544) 3Metal goods, engineering & vehicles industries (£1435) 4Other manufacturing industries (£1124) 5Construction (£1371) 6Distribution, hotels & catering (repairs) (£717) 7Transport & communication (£1347) 8Banking, finance, insurance, business services & leasing (£1499) 9Other services (£1144)

3 One-digit occupational wage structure in British Household Panel Survey data (Waves One to Eleven; N = 63 000). Average sample wage = £1163 per month (in real 1996 Pounds).

4 Standard Occupational Classification Major Groups: 1 Managers & administrators (£1947) 2 Professional occupations (£1793) 3 Associate professional & technical occupations (£1457) 4 Clerical & secretarial occupations (£878) 5 Craft & related occupations (£1206) 6 Personal & protective service occupations (£728) 7 Sales occupations (£633) 8 Plant & machine operatives (£1131) 9 Other occupations (£647) For comparison: Non-union (£1093) Union(£1377) Female (£862) Male (£1491)

5 LOOKING FOR LABOUR MARKET RENTS WITH SUBJECTIVE DATA Andrew E. Clark (PSE and IZA) Observation:There are industry and occupational wage differentials. Question:Are these rents or compensating differentials? or:Are high-wage jobs “better” than low-wage jobs? Data:Eleven waves of the British Household Panel Survey (BHPS). Method: Two stages. Correlate the estimated occupational coefficients from a wage equation with those from a utility (job satisfaction) equation. A positive correlation implies that (inexplicably) high-wage occupations are also (inexplicably) high satisfaction occupations, which sounds like rents. The same approach for the industry coefficients.

6 Results:OCCUPATION coefficients are POSITIVELY AND SIGNIFICANTLY correlated: especially for younger workers and for men. However, there are NO SIGNIFICANT CORRELATIONS at the INDUSTRY level. This result holds for both level and panel first-stage regressions. Interpretation:Occupational wage differences are partly rents; industry wage differences are not.

7 Supporting evidence: Use spell data. How do individuals get to the high-rent occupations? *From EMPLOYMENT (no surprise). *Via PROMOTION, rather than via voluntary mobility. *There is evidence of JOB-QUALITY LADDERS at the firm level.

8 Conclusion:  There are occupational rents. They aren’t competed away because firms control access to them, rather than workers.  Why do firms allow rents to exist? Perhaps to incite effort, as in tournament theory (evidence of job ladders)  Firms can only supply tournaments across occupations, not across industries. The industry wage structure then likely reflects other phenomena.

9 Wage and job satisfaction regressions. The utility function of worker i in occupation o, U io, is assumed to be linear in wages, job disamenities, D o, and a raft of other individual and job characteristics, X i : U io = ’X i +  w io -  D io (1) The compensating differential offered by firms for D o will be just enough to keep the worker on the same indifference curve: a unit of D is compensated by extra income of  / .

10 The wage of worker i in occupation o is argued, for simplicity, to depend on the same X’s as does utility in (1), compensation for the disamenities in that occupation, D o, and an occupation specific rent,  o : w io =  ’X i +  o + βD o (2) Note that worker homogeneity is assumed. From the utility function, the compensating differential for D is β=  / . Substituting for w io and β in (1) yields U io =  ’X i +  o (3)

11 I estimate equations (2) and (3). I have no information on  o or D o : these are picked up by two- digit occupational and industry dummies. In the wage equation, the estimated coefficients on these dummies will pick up both rents and disamenities (  o + βD o ); in the utility (job satisfaction) equation, the estimated coefficients will only reflect rents (  o ). The empirical strategy is therefore to see if the systematic differences in utility/job satisfaction across occupations are correlated with their counterparts in a standard wage equation. Correlate: the estimate of  o + βD o with that of  o. Strong correlation => the rent component of wage differentials is substantial. Weak correlation => the rent element,  o, is small.

12 Data BHPS Waves 1 to 11. Employees 16 to 65 only: 27 000 observations; 7000 different individuals. [] The proxy utility measure is overall job satisfaction (which predicts quits, absenteeism, and productivity). Measured on a one to seven scale:

13 BHPS: Overall Job Satisfaction ValueFrequencyPercentage Not Satisfied at All15211.9% 27722.9% 319667.3% 421778.1% 5571821.3% 61159543.2% Completely Satisfied7408815.2% ‑‑‑‑‑ - ‑‑‑‑‑‑ -- Total26837100.0%




17 Figure 1. The Relation between Estimated Coefficients in Wage and Job Satisfaction Regressions (Results for Men)





22 Note: Bold = significant at the five per cent level; Italic = significant at the ten per cent level.

23 INTERPRETATIONS Omitted variables (ability, unemployment rate etc)  The same results are found in both panel and level regressions  Controlling for the local unemployment rate doesn’t change anything.  Controlling for thirteen-level education doesn’t either.

24 INTERPRETATIONS Endogenous choice of occupation/heterogeneity Panel results are the same as level results. If there is sorting, we’d expect higher correlations for older workers (who have already sorted): we find the opposite. Try and control for tastes for income and hard work: marital status, number and ages of children, spouse’s labour force status, spouse’s income. Parents’ labour force status, parents’ occupation. A number of these attract significant estimates, but the correlation between the occupation coefficients in wage and job satisfaction regressions stays the same, as does that for industry coefficients.

25 I think that the occupational differences reflect rents..... Here’s why: Table 3. Getting to the Good Jobs: Occupations Use BHPS Spell data to see how individuals get to not high and high-quality jobs (as defined by negative or insignificant, and positive significant occupation dummy estimates in Table 1's job satisfaction regressions respectively).







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