Economic Models - Convex Optimization
Economic Models - Convex Optimization Economic Models - Convex Optimization
Time Varying Responses 63 Hence ( p(π i+1 |x i+1 ) = constant exp − 1 ) ... J i . 2 Since p(π i+1 |x i+1 ) is proportional to the likelihood function, by maximizing the conditional density function, we are also maximizing the likelihood in order to determine πi+1 ∗ ... . Note that minimization of J i, is equivalent to maximizing p(π i+1 |x i+1 ). To minimize ... J i, we expand Eq. (c) eliminating terms not containing π i+1 . Then, we differentiate with respect to π i+1 ′ and after equating to zero, we finally obtain (Lazaridis, 1980). πi+1 ∗ = π∗ i + (Q−1 1 − Q −1 1 G iQ −1 1 + H i+1 ′ Q−1 2 H i+1) −1 × H i+1 ′ Q−1 2 (x i+1 − H i+1 πi ∗ ). (d) Now, consider the composite matrix: Q −1 1 − Q −1 1 G iQ1 −1 where G i = (Si −1 + Q −1 1 )−1 . Considering the matrix identity of householder, we can write Q −1 1 − Q −1 1 (S−1 i + Q −1 1 )−1 Q −1 1 = (Q 1 + S i ) −1 Pi+1 −1 . Hence Eq. (d) takes the form: πi+1 ∗ = π∗ i + K i+1(x i+1 − H i+1 πi ∗ ) where K i+1 ,Si+1 −1 and P−1 i+1 are defined in Eqs. (21)–(23). It is recalled that H 0 is a null matrix, since no observations exist beyond period 1 in the estimation process. The same applies for the vector x 0 . Appendix B It is recalled that the model was estimated using FIML method. The FIML estimates are as follows (R 2 and adjusted R 2 refer to the corresponding 2 SLS estimates. Numbers in brackets are the corresponding t-statistics). Estimated Model 1. A t = 0.842Y t (3.48) + 55191.5 (4.87) + 0.024A t−1 − 1.319IR t + 1.051IR t−t − 284EXR t (1.74) (1.34) (1.16) (1.29) R 2 = 0.99, R 2 = 0.92, DW = 1.76, ρ = 0.27
64 Dipak R. Basu and Alexis Lazaridis 2. (Y t ) = A t + R t 3. (BD) t = (G t + LR t + PF t ) − (TY t + GBS t + AF t + FB t ) 4. PF t = 1148.80 + 0.169 CFB t−1 + 144.374 WIR t (1.48) (2.39) (1.89) 5. GBS t = 0.641G t (1.14) + 0.677G t−1 (1.41) + 1.591IR t (1.64) − 0.33AF t (0.23) R 2 = 0.89, R 2 = 0.84, DW = 2.36, ρ = 0.23 (1.51) 6. MD = MS 7. (MS) t = [(1 + CD t )/(CD t + RR t )](R t + NDA t ) 8. RR t = 0.008Y t (3.47) + 0.065 (2.72) 9. CD t = 0.4391IR t (−1.49) 10. MD t = 2.733RR t (−2.52) − 0.002Y t−1 (−1.84) + 1.2571R t (1.87) + 2.7031R t−1 (1.88) − 0.003T (2.87) R 2 = 0.86, R 2 = 0.79, DW = 2.88, ρ = 0.26 (1.23) − 0.0057T (−6.269) + 0.193 (11.95) + 0.158CD t−1 + 0.0007Y t + 0.009Y t−1 (1.16) (1.56) (1.73) R 2 = 0.94, R 2 = 0.92, DW = 1.22, ρ = 0.64 (4.21) − 2.19IR t (−0.24) + 1.713IR t−1 + 1.275Y t (2.17) (6.67) − 113335.0 (−0.088) R 2 = 0.86, R 2 = 0.81, DW = 1.92, ρ = 0.26 (1.31) 11. IR t = 0.413MD t−1 (1.93) + 0.406Y t−1 (1.56) 12. P t = 0.0004A t (−5.71) − 0.814IR t−1 + 8.656CI t − 1.351CI t−1 (1.403) (1.68) − 7.02 (−1.84) R 2 = 0.98, R 2 = 0.95, DW = 2.48,ρ = 0.58 (3.21) + 0.0002A t−1 + 0.105IMC t (1.77) (1.48) + 0.421P t−1 (3.79) R 2 = 0.98, R 2 = 0.93, DW = 2.09,ρ = 0.48 13. IMC t = 5.347 + 19.352WPM t + 9.017EXR t (1.34) (2.03) (0.97) R 2 = 0.98, R 2 = 0.97, DW = 2.07, ρ = 0.31 (1.37) 14. R t = X t − IM t + K t + PFT t + FB t − PF t + AF t + 32.895 (1.87)
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Time Varying Responses 63<br />
Hence<br />
(<br />
p(π i+1 |x i+1 ) = constant exp − 1 )<br />
...<br />
J i .<br />
2<br />
Since p(π i+1 |x i+1 ) is proportional to the likelihood function, by maximizing<br />
the conditional density function, we are also maximizing the likelihood<br />
in order to determine πi+1 ∗ ...<br />
. Note that minimization of J i, is equivalent to<br />
maximizing p(π i+1 |x i+1 ). To minimize ...<br />
J i, we expand Eq. (c) eliminating<br />
terms not containing π i+1 . Then, we differentiate with respect to π<br />
i+1 ′ and<br />
after equating to zero, we finally obtain (Lazaridis, 1980).<br />
πi+1 ∗ = π∗ i + (Q−1 1<br />
− Q −1<br />
1 G iQ −1<br />
1<br />
+ H i+1 ′ Q−1 2 H i+1) −1<br />
× H i+1 ′ Q−1 2 (x i+1 − H i+1 πi ∗ ). (d)<br />
Now, consider the composite matrix:<br />
Q −1<br />
1<br />
− Q −1<br />
1 G iQ1 −1 where G i = (Si<br />
−1 + Q −1<br />
1 )−1 .<br />
Considering the matrix identity of householder, we can write<br />
Q −1<br />
1<br />
− Q −1<br />
1 (S−1 i<br />
+ Q −1<br />
1 )−1 Q −1<br />
1<br />
= (Q 1 + S i ) −1 Pi+1 −1 .<br />
Hence Eq. (d) takes the form:<br />
πi+1 ∗ = π∗ i + K i+1(x i+1 − H i+1 πi ∗ )<br />
where K i+1 ,Si+1 −1 and P−1<br />
i+1<br />
are defined in Eqs. (21)–(23).<br />
It is recalled that H 0 is a null matrix, since no observations exist beyond<br />
period 1 in the estimation process. The same applies for the vector x 0 .<br />
Appendix B<br />
It is recalled that the model was estimated using FIML method. The FIML<br />
estimates are as follows (R 2 and adjusted R 2 refer to the corresponding 2<br />
SLS estimates. Numbers in brackets are the corresponding t-statistics).<br />
Estimated Model<br />
1. A t = 0.842Y t<br />
(3.48)<br />
+ 55191.5<br />
(4.87)<br />
+ 0.024A t−1 − 1.319IR t + 1.051IR t−t − 284EXR t<br />
(1.74) (1.34) (1.16) (1.29)<br />
R 2 = 0.99, R 2 = 0.92, DW = 1.76, ρ = 0.27