28
and solving for x, we can show that the maximum effect reached at the inflation level of
1.586/0.706 = 2.246 %; and the maximum value would be 1.781%.
The marginal effect of inflation depends on the initial value:
1.586
– 0.353
1.586
– 0.353
In the text chart, we plot the marginal effect of changes in inflation rates (red line), while
assuming an initial inflation rate of 0.00% as in our policy scenario. The chart shows an
initially increasing, but then
diminishing marginal effect.
Moreover, the marginal effect
becomes negative (i..e further
inflation reduces inclusive growth)
at around 4.5%. Note that, because
the specified curve is symmetric, the
marginal effect would decay off at
the same distance from the optimal
level. In this case, it is
2.246
2.246
0 4.492%.
The policy scenario we considered is
the initial value of 0.00% and the
targe rate of 2.00% (text chart, green
line). With an increase of 2.00%
points, the marginal effect on the
inclusive growth is 1.76%, slighlty
less than the value at the optimal level.
29
Appendix D. Causality Direction between Inflation and Growth
To test endogeneity, we run simple bilateral regressions between growth and inflation:
y
a y
‐
a y
‐
b m
‐
b m
‐
μ v
where is the dependent variable and is the (supposedly endogenous) explanatory
variables. Note that this is not equivalent to a conventional Grange causilitu test because: the
lag is not chosen by statistical significance, but limited by the data availability (l=2);
regressions are run separately; and the specification contains the fixed effect for each
prefecture.
The result is shown in the table below.
Dependent variable:
Growth
Inflation
(1)
(2)
lag(dys, 1)
-0.461
***
0.080
**
(0.110)
(0.039)
lag(dys, 2)
-0.078
0.094
**
(0.104)
(0.037)
lag(Inflation, 1)
2.052
***
0.962
***
(0.251)
(0.090)
lag(Inflation, 2)
1.431
***
0.816
***
(0.093)
(0.033)
Observations
144
144
R
2
0.748
0.918
Adjusted R
2
0.478
0.587
F Statistic (df = 4; 92) 68.230
***
258.300
***
Note:
*
p<0.1;
**
p<0.05;
***
p<0.01
Both variables are good leading indicator of the other both at the lag of 1 and 2, but the
coefficients on the impact of inflation on growth tend to be larger than those of the impact on
griwth on inflation.
30
We have also estimated the same model as in the becnhamrk case, btu with with lagged (l=1)
inflation (5 year averages) as an instrument variable (Balestra & Varadharajan-
Krishnakumar, 1987). The results are shown below, and are broadly consistens with those
discussed in the main text.
Table 1
Results for All Income, IV
Dependent variable:
dys
dy
dw
(1)
(2)
(3)
Inflation (%)
4.707
***
4.592
***
0.051
(1.154) (1.071) (0.259)
Inflation, squared
-0.876
***
-0.832
***
-0.034
(0.195) (0.181) (0.044)
Part- to Full-time job opennings (%) 0.031
0.023
0.007
(0.038) (0.035) (0.009)
Female labor force participation (%) 0.270
*
0.225
*
0.042
(0.137) (0.127) (0.031)
Labor input growth (%)
0.156
0.136
0.019
(0.291) (0.270) (0.065)
Initial GDP per capita
-5.476
***
-4.737
***
-0.707
*
(1.812) (1.683) (0.407)
Elderly index
0.450
***
0.429
***
0.014
(0.153) (0.142) (0.034)
Observations
235
235
235
R
2
0.486
0.539
0.105
Adjusted R
2
0.374
0.415
0.081
F Statistic (df = 7; 181)
5.173
***
7.330
***
3.021
***
Not
e:
*
p<0.1;
**
p<0.05;
***
p<0.01
31
Results for Working-age Income, IV
Dependent variable:
dys.work dy.work dw.work
(1)
(2)
(3)
Inflation (%)
4.926
***
4.371
***
0.534
(1.226) (1.047) (0.324)
Inflation, squared
-0.852
***
-0.743
***
-0.106
*
(0.207) (0.177) (0.055)
Part- to Full-time job opennings (%) 0.025
0.014
0.011
(0.040) (0.034) (0.011)
Female labor force participation (%) 0.338
**
0.250
**
0.088
**
(0.146) (0.124) (0.038)
Labor input growth (%)
-0.020
0.018
-0.039
(0.309) (0.264) (0.082)
Initial GDP per capita
-4.770
**
-3.545
**
-1.230
**
(1.926) (1.645) (0.509)
Elderly index
0.497
***
0.417
***
0.079
*
(0.162) (0.139) (0.043)
Observations
235
235
235
R
2
0.444
0.514
0.007
Adjusted R
2
0.342
0.396
0.005
F Statistic (df = 7; 181)
-0.283
5.466
***
-4.416
Note:
*
p<0.1;
**
p<0.05;
***
p<0.01
32
Appendix E. Contributions of regressors to variation in equity.
In the text table below me represent various measures of how much of the variation in the
equity index is explained by the various regressors. The top three variables for each measure
are denoted by ***.
Standardized Regression Coefficients show the expected change of the dependent variable in
standard deviations with respect to one standard deviation change in the explanatory variable.
(e.g. one standard deviation change in FLP is associated with a 0.373 standard deviation
change in equity index growth).
Semi-Partial Correlation Coefficients measure the unique contribution of each explanatory
variable in explaining the variations of the dependent variable. The proportion of the
variation that is jointly explained by multiple variables is not accounted for in this measure
(i.e. if all the explanatory variables are independent of each other, the set of semi-partial
correlation coefficients sum up to the R^2 of the model.)
Extra Sum of Squares is simply the amount of sum of squared residuals reduced by removing
one variable from the full model. (e.g. by removing inflation the sum of squared residuals is
increased by 0.707, by removing inflations squared it is increase by 0.321). Note that they do
not sum up to the total sum of squared residuals.
Contributions of regressors to variation in equity.
Standardized
Regression
Coefficients
Semi-Partial
Correlation
Coefficients
Extra Sum
of Squares
Inflation
-0.089 0.005***
0.707***
Inflation, squared
-0.056 0.006***
0.321***
Job Openings
0.132*** 0.001 0.089
FLP
0.373*** 0.007*** 0.254
Labor Growth
0.069 0.0005
0.032
GDP PC
-0.58*** 0.004
0.757***
Elderly Index
0.079 0.0001
0.017
- 0.0236
-
33
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