Evaluation of the Australian Wage Subsidy Special Youth ...
Evaluation of the Australian Wage Subsidy Special Youth ... Evaluation of the Australian Wage Subsidy Special Youth ...
82 SYETP at 53.6 per cent, 45.6 per cent for repeat SYETP and 52.4 per cent for extended SYETP. A small share between 5-6 per cent was in part time employment. Fulltimeemployment prior to SYETP was lower for SYETP Private at 52 per cent, so before controlling for individual characteristics they were more likely to hold a job after than before the programme (Baker (1984) p16, Tables A4 and 5.1). For other SYETP, post programme employment was lower or the same. A probit model of response to the survey was found to indicate response bias might be present. 55 The various programme dummies were significant in modelling response, where response was a full response with no missing items. The post-programme full-time employment outcome was modelled using a variable with 3 categories: continuous employment, including those retained in the job and those who left after the subsidy but got a job within a month; non-continuous employment, including those retained in the job for only 1 month after subsidy expiry but who later lost it by the survey date, and those who left after the subsidy and took longer than one month to find a job; no employment, including unemployed, education or other states of not in the labour force. This variable combined holding a job since the programme and the durability of the jobs held since programme, as well as the job search success, to perhaps to reflect employability. Table 2.18 shows the distribution of this variable for the various SYETP. It can be seen for example, that the continuous full-time work category for SYETP private is much lower at 41.1 per cent than the share in employment at interview (60.6 per cent). However, about 80 per cent of SYETP private participants had held some full-time employment. The employment variable with three categories (no employment, continuous and noncontinuous employment) was then modelled as an ordered probit, as if it were count data. The selection process onto programme participation was not modelled. However, the ordered employment probit was adjusted for non-response using the Heckman model. To adjust for non-response, the non-response model was used “…to estimate a correction factor LAMBDA…included as an additional independent variable”, and this variable was 55 Baker (1984) p49 Table A11 Variables included age, sex, unemployment (weeks in 52 week year before program entry), multiple program participation, dismissal, voluntary withdrawal, 10 program dummies with SYETP private as Base, state dummies. State dummies were not statistically significant.
83 included in the employment model. This is the Heckman selection correction model where the lambda is the inverse mills ratio. The employment model had the variables age, sex, year left school (but not qualifications), post-school formal training (any post-school qualifications), a post-school job (pre-programme), weeks unemployment (weeks in 52 week year before programme entry), multiple programme participation, dismissal, voluntary withdrawal, 10 programme dummies with SYETP private as base, state dummies and the LAMBDA correction factor. The response model used a subset of these variables, so that the exclusion restriction variables were year left school, post school formal training and post school job (pre-programme). No additional results were presented showing the sensitivity of the employment model to whether or not nonresponse was accounted for, so it is not clear whether the additional Heckman selection model performed better than a simpler model without nonresponse. Baker estimated predicted probabilities for employment for various subgroups using the model outcomes. Predicted probabilities were estimated for the eligibility period of 17 weeks unemployment in the past 52 weeks, for a participant who left school in year 10/11, did post-school training, took part in no other programme and completed the programme of participation. They found that SYETP private generally performed better than education based programmes, but did no better than other SYETP, and was significantly worse than extended SYETP. The results are shown below for SYETP in Table 2.19. It can be seen that the ‘out of work’ outcome had a very low probability for all types of SYETP. Table 2.18 Baker (1984) Post-programme full-time employment outcome Continuous fulltime work Non- Continuous fulltime work Retained Not-retained Total 21.1 14.3 35.5 33.7 30.8 SYETP Commonwealth SYETP private 34.9 6.3 41.1 38.4 20.4 2nd SYETP 24.3 7.3 31.6 41.2 27.2 Extended SYETP 37.1 5.5 42.6 30.6 26.8 Source: Baker (1984) p19 Table 5.2 May 1982 post-programme Survey of participants Out of work
- Page 47 and 48: 31 limited applications, such as fo
- Page 49 and 50: 33 who participated. It was conclud
- Page 51 and 52: 35 term unemployed for over 12 of t
- Page 53 and 54: 37 importance of the subsidy second
- Page 55 and 56: 39 differences in characteristics t
- Page 57 and 58: 41 Matching methods are theoretical
- Page 59 and 60: 43 2.2 SYETP implementation As SYET
- Page 61 and 62: 45 In July1978, the subsidy was cal
- Page 63 and 64: 47 In January 1979, variations were
- Page 65 and 66: 49 benefits were paid at a slightly
- Page 67 and 68: 51 2.2.3 SYETP operation Earlier re
- Page 69 and 70: 53 ceiling constraints’ applied t
- Page 71 and 72: 55 Award Conditions for employment
- Page 73 and 74: 57 Harris (2001) claims that during
- Page 75 and 76: 59 display boards listed details of
- Page 77 and 78: 61 restriction was used. If there w
- Page 79 and 80: 63 to the end of the 1980’s. An o
- Page 81 and 82: 65 for teens overall had risen, emp
- Page 83 and 84: 67 for Australia using data from th
- Page 85 and 86: 69 training, can provide a form of
- Page 87 and 88: 71 employer survey estimates were t
- Page 89 and 90: 73 provisions for SYETP and extende
- Page 91 and 92: 75 withdrawals occurred at similar
- Page 93 and 94: 77 Table 2.17 State usage of progra
- Page 95 and 96: 79 2.3.1 Stretton (1982, 1984) 53 S
- Page 97: 81 Stretton attributed the success
- Page 101 and 102: 85 completers. Their argument was t
- Page 103 and 104: 87 was an issue for the data. Unlik
- Page 105 and 106: 89 Table 2.21 Richardson (1998) Est
- Page 107 and 108: 91 2.3.5 General discussion Some ge
- Page 109 and 110: 93 Controlling for differences in i
- Page 111 and 112: 95 taken by a previous researcher a
- Page 113 and 114: 97 If employability is assumed to b
- Page 115 and 116: 99 suitability of the underlying as
- Page 117 and 118: 101 Heckman, Lalonde and Smith (199
- Page 119 and 120: 103 effect on employment relative t
- Page 121 and 122: 105 Table 3.1, Part A Employment eq
- Page 123 and 124: 107 (-1.80) (-1.80) Tradesperson -0
- Page 125 and 126: 109 duration of Pre-June 1984 unemp
- Page 127 and 128: 111 4: Study 2 Propensity score mat
- Page 129 and 130: 113 Propensity score matching provi
- Page 131 and 132: 115 4.2 Propensity score matching m
- Page 133 and 134: 117 covariates that influence the a
- Page 135 and 136: 119 (7) E(Y c | D=1) = E P(X) {E[Y
- Page 137 and 138: 121 For CIA to be plausible, a ‘r
- Page 139 and 140: 123 employment and programme partic
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- Page 143 and 144: 127 4.6 Distribution of the propens
- Page 145 and 146: 129 Figure 4.3 Histograms of estima
- Page 147 and 148: 131 Table 4.5 Summary statistics fo
82<br />
SYETP at 53.6 per cent, 45.6 per cent for repeat SYETP and 52.4 per cent for extended<br />
SYETP. A small share between 5-6 per cent was in part time employment. Fulltimeemployment<br />
prior to SYETP was lower for SYETP Private at 52 per cent, so before<br />
controlling for individual characteristics <strong>the</strong>y were more likely to hold a job after than<br />
before <strong>the</strong> programme (Baker (1984) p16, Tables A4 and 5.1). For o<strong>the</strong>r SYETP, post<br />
programme employment was lower or <strong>the</strong> same.<br />
A probit model <strong>of</strong> response to <strong>the</strong> survey was found to indicate response bias might be<br />
present. 55 The various programme dummies were significant in modelling response,<br />
where response was a full response with no missing items. The post-programme full-time<br />
employment outcome was modelled using a variable with 3 categories: continuous<br />
employment, including those retained in <strong>the</strong> job and those who left after <strong>the</strong> subsidy but<br />
got a job within a month; non-continuous employment, including those retained in <strong>the</strong> job<br />
for only 1 month after subsidy expiry but who later lost it by <strong>the</strong> survey date, and those<br />
who left after <strong>the</strong> subsidy and took longer than one month to find a job; no employment,<br />
including unemployed, education or o<strong>the</strong>r states <strong>of</strong> not in <strong>the</strong> labour force. This variable<br />
combined holding a job since <strong>the</strong> programme and <strong>the</strong> durability <strong>of</strong> <strong>the</strong> jobs held since<br />
programme, as well as <strong>the</strong> job search success, to perhaps to reflect employability. Table<br />
2.18 shows <strong>the</strong> distribution <strong>of</strong> this variable for <strong>the</strong> various SYETP. It can be seen for<br />
example, that <strong>the</strong> continuous full-time work category for SYETP private is much lower at<br />
41.1 per cent than <strong>the</strong> share in employment at interview (60.6 per cent). However, about<br />
80 per cent <strong>of</strong> SYETP private participants had held some full-time employment.<br />
The employment variable with three categories (no employment, continuous and noncontinuous<br />
employment) was <strong>the</strong>n modelled as an ordered probit, as if it were count data.<br />
The selection process onto programme participation was not modelled. However, <strong>the</strong><br />
ordered employment probit was adjusted for non-response using <strong>the</strong> Heckman model. To<br />
adjust for non-response, <strong>the</strong> non-response model was used “…to estimate a correction<br />
factor LAMBDA…included as an additional independent variable”, and this variable was<br />
55 Baker (1984) p49 Table A11 Variables included age, sex, unemployment (weeks in 52 week year before<br />
program entry), multiple program participation, dismissal, voluntary withdrawal, 10 program dummies with<br />
SYETP private as Base, state dummies. State dummies were not statistically significant.