Dipankar Biswas, Sanjay Singh
and Arti Sinha*
Maintaining low and stable inflation with sustainable growth is the prime objective of
any monetary authority. To achieve the prime goal, reliable forecast of macroeconomic
variables play an important role. In this paper, the authors tried to develop a forecasting
model for inflation as well as IIP growth in a multivariate time series Bayesian framework,
known as Bayesian Vector Autoregressive (BVAR) Model. The main advantage of using this
model is the incorporation of prior information which may boost the forecasting performance
of the model. Using the quarterly data on WPI, M1 and IIP during the period of first quarter
of 1994-95 (Q1: 1994-95) to last quarter of 2007-08 (Q4: 2007-08), a VAR was developed
and subsequently using Minnesota prior or Litterman’s prior proposed by Litterman in 1980,
a BVAR model was developed. Based on the comparison of forecasting performance of VAR
and BVAR model, measured in terms of out-of-sample percentage root mean square error, it
is found that BVAR model performed better than VAR model in case of inflation as well as
IIP growth forecast.
JEL Classification : C1, C3, E2, E3.
Keywords : inflation, Output, VAR, Bayesian VAR, Minnesota prior.
Introduction
Undoubtedly, maintaining inflation at low and stable rate which
bust production environment without hearting common people is
primary goal of any monetary authority at the globe. In the process of
achieving this prime goal, while making monetary policy, a lot of
information on monetary and fiscal variables are required. Along with these inputs, the reliable forecasts of macro-economic variables
undoubtedly have significant policy implications. It is therefore, the
search for better forecasting techniques to get reliable forecast is
always vital. To access the general price situation, which is likely to
be appeared in the next coming few months, the frequently used
forecasting models are univariate time series models like autoregressive
model, moving average model, autoregressive moving average model,
etc. or multivariate times series model. The merit of using multivariate
time series model is, along with incorporating past information of the
target variable, it allows to incorporate inter-temporal interdependence
of other variables for improving the forecasting performance. The
commonly used multivariate time series model is vector autoregressive
(VAR) model. But, the major setback of this model is the problem of
overparameterisation. By the nature of the model, it requires to
estimate large number of parameters which leads to large standard
error. So, if some restriction can be imposed on the parameters then
the performance of the model should be improved.
The facility of imposing restrictions is available in Bayesian
Statistics by the way of prior information on parameters/coefficients.
As, the name itself says about prior information, it is the information
about the parameters which come before the experiment, by the way of
other experiments, personal belief of the forecaster, etc., and then
assigning probability distribution to each coefficients of the model. This
Bayesian VAR (BVAR) approach provides more accurate forecasts
(Litterman (1980), Kinal and Ratner (1986)). BVAR is also superior to
VAR since it is robust to the choice of national variables, even when
misspecified national variables are included (Shoesmith, 1990). Hence,
a modified VAR restricting certain parameters is sometimes preferred.
In general, the prior being used for BVAR is Minnesota prior or
Litterman’s prior proposed by Litterman in 1980. Some important
studies being done using Bayesian VAR are for Minnesota (Litterman,
1980), New York state (Kinal and Ratner 1986), Texas (Gruben and
Long 1988), Louisiana (Gruben and Hayes 1991), Iowa (Otrok and
Whiteman 1998) and Philadelphia Metropolitan Area (Crone and
McLaughlin 1999).
In this project, the idea is to develop a Bayesian Vector
Autoregressive (BVAR) model for Indian Economy by allowing
possibility of interactions between the important macroeconomic
variables. Here, at the first stage, we have developed a VAR model for
the two most important macroeconomic variables viz. industrial output
growth and inflation of the economy. Next, the VAR model is modified
to make a BVAR model. Lastly, a comparative study between the VAR
and BVAR models is done based on the out-of-sample forecasting
performance.
The rest of the paper is organized as follows. Section I gives the
literature review. A short description on VAR process and BVAR
process and on Litterman’s prior is given in Section II. Section III
presents the data, variables used and period of study. Section IV
describes the empirical results. Finally, the concluding remarks are
presented in Section V.
Section I
Literature Review
The comparative analysis of short-run forecasting methods used
in this present work has been recurrent in the econometric literature.
Three main trends were then distinguished. In the 1950s, the first
forecasts were released to analyze business cycles and enlighten
public decisions. As these were successfully used in the ‘60s and the
‘70s, forecasting developed later mainly through macroeconometric
models, which were carried out by many economists (Mincer and
Zarnowitz (1969), Makridakis & Hibon (1979), Fair (1979),
Fonteneau (1982), Bodkin, Klein & Marwah (1990)). However,
critics arose in the late ‘70s, (Lucas (1970), Kydland & Prescott
(1977), Sims (1980)), saying that the forecasts were inaccurate and
unable to anticipate the big crises of seventh and eighth decades of
twentieth century. This period put an end to the golden age of
forecasting based on econometric models and favoured the emergence
of new methodological approaches.
Some works broke up with the traditional approach by offering
diverse methods to study time series data (Kaman filter, Box-Jenkins
methodology, the VAR modelling, state-space models). At the end
of the ‘80s, empirical studies on these methods flourished,
questioning their effectiveness and performances faced with the
macroeconomic models (Kling and Blesser (1985), McNees (1986),
Makridakis (1986), Wallis (1989), Aoki (1990). In short, this second
trend showed that the methods based on time series data gave
comparable or even superior results to the traditional macreconometric
models.
The third trend corresponds to the present time. It started with
questions about the non-stationarity of the series and their long-run
evolution. The answers to these questions aroused a tremendous interest
in econometric research. It consequently led to a large diversity of
works on economic variables in 1990s. It is however too soon to measure
the effectiveness and significance of these current methods, which
remain to be improved.
The use of VAR models has been recommended by Sims (1980) as
an efficient alternative to verify causal relationships in economic
variables and to forecast their evolution. On the theoretical level, this
approach has its foundation in the work of Wold (1938), Box and Jenkins
(1980) and Tiao and Box (1981). Given the vector of variables, the
classical VAR model explains each variable by its own past values and
the past values of all other variables by a well-defined relation. For
macroeconomic forecasting, VAR has become a standard tool. VARs
produce dynamic forecasts that are consistent across equations and
forecast horizons.
The issue which has entailed for a long time the controversy
between the supporters and detractors of the Bayesian procedure is
the estimation of the parameters of a model, either by using the
statistical inference techniques or, on the contrary, by taking into
account the previous knowledge of the economic system. The
application of this procedure implies that an a priori probability has
to be chosen and it can only be applied to models with a finite number
of parameters. Yet, since most of the macroeconomic variables are
from stochastic tendencies, the specification of their distribution
turns out to be necessary. Usually, the hypothesis of normality for the
coefficients is adopted since, in most cases, the underlying economic
theory has little influence on the distribution of errors. In thefield of
multivariate modelling, Litterman suggested the use of the Bayesian
procedure (1980) as an efficient way of avoiding some of the problems
posed by Sims VAR models. The over-parametrisation is mainly the
cause of these problems. Indeed, even if the reduced-size systems are
involved, too many parameters have to be considered, which turns
out to be non-significant after applying the hypothesis tests. Thus, it
is necessary to put forward that the out-of-sample forecasts obtained
by means of a standard VAR model depend a lot on the number of
lags, even though the values observed and calculated are very close
on the estimation period. In order to bypass these difficulties,
Litterman (1980) introduces some a-priori knowledge in the
formulation of his model by means of a distribution of probabilities.
The primary focus of monetary policy, both in India and
elsewhere, has traditionally been the maintenance of a low and stable
rate of aggregate price inflation along with sustainable economic
growth. The underlying justification for this objective is the widespread
consensus supported by numerous economic studies that inflation is
costly insofar as it undermines real, wealth-enhancing economic
activity. If anything, this consensus is probably stronger today than it
ever has been in the past. Indeed, it could be argued that much of the
improvement in Indian living standards which has taken place over
the last two decades would not have been achieved without the
establishment of a credible low inflation environment.
This paper focuses mainly on BVAR models. Over the past
twenty years, the BVAR approach has gained widespread acceptance
as a practical tool to provide reasonably accurate macroeconomic
forecasts when compared to conventional macroeconomic models or
alternative time series approaches.
Section II
Methodology : An Overview
Vector Autoregressive Model :
In notational form, mean-adjusted VAR(p) model (VAR model of
order p) can be written as
Under the standard VAR, coefficient vector β is unknown but fixed
which has to be estimated.
Bayesian Vector Autoregressive(BVAR) Model:
On the other hand, in BVAR model the coefficients β’s are
considered as variables which some known distribution known as prior
distribution. The parameter of prior distribution is known as
hyperparameter. In this project, we have used Minnesota prior or
Litterman’s prior proposed by Litterman in 1980. Under this prior,
parameter vector β has a prior multivariate normal distribution withknown mean β* and covariance matrix Vβ, hence the prior density is
written as
Section III
Selected of Variables and Time Period of the Study
In India, the measurement of general price situation of the country
as a whole is based on Wholesale price Index (WPI), we have used
following variables in our study:
- Wholesale Price Index (WPI)
- Index of Industrial Production (IIP), and
- Narrow Money (M1).
We have used quarterly data during the period of first quarter of
1994-95 (Q1 : 1994-95) to last quarter of 2007-08 (Q4 : 2007-08). The
model is fitted based on data till Q4 : 2006-07, whereas, data for
remaining period is being used for testing the model performance.
Before developing the model logarithmic transformation has been
used. Whereas, to adjust with seasonality, seasonal dummies are used.
Section IV
Empirical Analysis
Stationary: The Augmented Dickey Fuller test is used for testing
stationarity at the level and at first difference. Based on the results of the
test statistics (Appendix 1), it can be observed that the variables are
seems to be stationary at first difference.
Selection of Order of VAR: For the purpose of selecting order of
VAR, the Minimum Information Criteria as well as Univariate Model
White Noise Diagnostics are being used and based on these criteria, the
order of VAR is found to be two.
The results of VAR(2) is given in the Appendix 2. Based on these
results, it can be observed that the diagnostics results of this model are
appears to be satisfactory. And out of sample percentage root mean square error (PRMSE) for WPI for four quarters is 1.4932 percent,
whereas, for IIP, it is 4.2508 percent.
Selection of values of lambda and theta in Litterman prior :
Here, since the VAR model is developed at difference of the variables,
therefore, the absolute value of the parameters would be less then one
and hence mean of prior distribution is taken as zero, whereas, the
degree of closeness of parameters to the prior mean can be controlled
by suitable values of lambda and theta. Further, for selecting the a
suitable values for lambda and theta, we have tried various combination
for these parameters between 0 to 1 and based on PRMSE (Appendix
3), we found that lambda=0.3 and theta=0.9 are suitable values for
BVAR(2). Therefore, BVAR(2) with lambda=0.3 and theta=0.9 was
fitted and results of the model is given in Appendix 4.
From the results, given in the table 1, it can be observed that, out
of sample PRMSE has been reduced while using BVAR in both the
cases i.e. for WPI as well as IIP.
Table 1 : Comparison of the Models |
Model |
Out of Sample PRMSE |
WPI |
IIP |
VAR(2) |
1.4932 |
4.2508 |
BVAR(2) |
1.4400 |
3.6055 |
Section V
Concluding Remarks
In this project, with the objective of getting better forecast of
inflation as well as IIP growth, quarterly data on WPI, IIP and M1 since
first quarter of 1994-95 to fourth quarter of 2007-08 were used and we
developed a VAR as well as Bayesian VAR (BVAR) model for forecasting
the target variables. Further, based on the comparison of performance
of these two models, it is found that the forecasting performance,
measured in terms of out-of-sample percentage root mean square error
of VAR model being used for forecasting inflation as well as IIP growth,
has improved by applying Bayesian technique.
Appendix 1 : Unit Root Test
Augmented Dickey-Fuller Unit Root Tests (Level) |
Variable: lwpi |
Type |
Lags |
Rho |
Pr < Rho |
Tau |
Pr < Tau |
Zero Mean |
1 |
0.1238 |
0.7069 |
5.23 |
0.9999 |
|
2 |
0.1205 |
0.7060 |
5.55 |
0.9999 |
|
3 |
0.1175 |
0.7052 |
5.63 |
0.9999 |
|
4 |
0.1118 |
0.7038 |
4.08 |
0.9999 |
Single Mean |
1 |
-0.3863 |
0.9315 |
-0.86 |
0.7923 |
|
2 |
-0.2066 |
0.9428 |
-0.62 |
0.8555 |
|
3 |
-0.1395 |
0.9466 |
-0.56 |
0.8704 |
|
4 |
0.0838 |
0.9581 |
0.31 |
0.9765 |
Trend |
1 |
-44.0181 |
<.0001 |
-4.98 |
0.0010 |
|
2 |
-42.7256 |
<.0001 |
-4.01 |
0.0148 |
|
3 |
-34.3860 |
0.0005 |
-3.27 |
0.0827 |
|
4 |
-82.5674 |
<.0001 |
-3.24 |
0.0892 |
Variable : liip |
Type |
Lags |
Rho |
Pr < Rho |
Tau |
Pr < Tau |
Zero Mean |
1 |
0.1238 |
0.7069 |
5.23 |
0.9999 |
|
2 |
0.1205 |
0.7060 |
5.55 |
0.9999 |
|
3 |
0.1175 |
0.7052 |
5.63 |
0.9999 |
|
4 |
0.1118 |
0.7038 |
4.08 |
0.9999 |
Single Mean |
1 |
-0.3863 |
0.9315 |
-0.86 |
0.7923 |
|
2 |
-0.2066 |
0.9428 |
-0.62 |
0.8555 |
|
3 |
-0.1395 |
0.9466 |
-0.56 |
0.8704 |
|
4 |
0.0838 |
0.9581 |
0.31 |
0.9765 |
Trend |
1 |
-44.0181 |
<.0001 |
-4.98 |
0.0010 |
|
2 |
-42.7256 |
<.0001 |
-4.01 |
0.0148 |
|
3 |
-34.3860 |
0.0005 |
-3.27 |
0.0827 |
|
4 |
-82.5674 |
<.0001 |
-3.24 |
0.0892 |
Variable : lm1 |
Type |
Lags |
Rho |
Pr < Rho |
Tau |
Pr < Tau |
Zero Mean |
1 |
0.1374 |
0.7101 |
6.13 |
0.9999 |
|
2 |
0.1319 |
0.7087 |
7.19 |
0.9999 |
|
3 |
0.1262 |
0.7073 |
8.90 |
0.9999 |
|
4 |
0.1222 |
0.7062 |
3.28 |
0.9996 |
Single Mean |
1 |
0.3323 |
0.9688 |
0.73 |
0.9917 |
|
2 |
0.4188 |
0.9719 |
1.47 |
0.9990 |
|
3 |
0.4760 |
0.9737 |
3.33 |
0.9999 |
|
4 |
0.5584 |
0.9762 |
2.55 |
0.9999 |
Trend |
1 |
-9.3281 |
0.4442 |
-1.57 |
0.7891 |
|
2 |
-0.5215 |
0.9915 |
-0.14 |
0.9927 |
|
3 |
2.9137 |
0.9999 |
1.73 |
0.9999 |
|
4 |
1.0159 |
0.9985 |
0.35 |
0.9984 |
Augmented Dickey-Fuller Unit Root Tests (Difference=1) |
Variable: lwpi |
Type |
Lags |
Rho |
Pr < Rho |
Tau |
Pr < Tau |
Zero Mean |
1 |
-16.6621 |
0.0028 |
-2.95 |
0.0040 |
|
2 |
-9.9214 |
0.0245 |
-2.19 |
0.0285 |
|
3 |
-3.4208 |
0.1989 |
-1.57 |
0.1090 |
|
4 |
-2.2352 |
0.3006 |
-1.20 |
0.2062 |
Single Mean |
1 |
-99.6940 |
0.0004 |
-6.79 |
0.0001 |
|
2 |
-1124.78 |
0.0001 |
-6.42 |
0.0001 |
|
3 |
-114.865 |
0.0001 |
-4.43 |
0.0008 |
|
4 |
-316.520 |
0.0001 |
-3.93 |
0.0036 |
Trend |
1 |
-100.378 |
0.0001 |
-6.75 |
<.0001 |
|
2 |
-1321.11 |
0.0001 |
-6.37 |
<.0001 |
|
3 |
-106.584 |
0.0001 |
-4.29 |
0.0072 |
|
4 |
-241.817 |
0.0001 |
-3.84 |
0.0232 |
Variable: liip |
Type |
Lags |
Rho |
Pr < Rho |
Tau |
Pr < Tau |
Zero Mean |
1 |
-244.186 |
0.0001 |
-11.26 |
<.0001 |
|
2 |
623.2370 |
0.9999 |
-7.67 |
<.0001 |
|
3 |
-2.7100 |
0.2542 |
-1.23 |
0.1977 |
|
4 |
-3.4941 |
0.1940 |
-1.64 |
0.0946 |
Single Mean |
1 |
-389.858 |
0.0001 |
-14.13 |
0.0001 |
|
2 |
115.7601 |
0.9999 |
-18.48 |
0.0001 |
|
3 |
-20.2941 |
0.0053 |
-2.61 |
0.0973 |
|
4 |
-38.5153 |
0.0004 |
-3.23 |
0.0241 |
Trend |
1 |
-388.594 |
0.0001 |
-13.97 |
<.0001 |
|
2 |
116.0946 |
0.9999 |
-18.38 |
<.0001 |
|
3 |
-21.3430 |
0.0283 |
-2.67 |
0.2548 |
|
4 |
-39.1565 |
<.0001 |
-3.43 |
0.0602 |
Variable: lm1 |
Type |
Lags |
Rho |
Pr < Rho |
Tau |
Pr < Tau |
Zero Mean |
1 |
-21.4662 |
0.0005 |
-3.06 |
0.0029 |
|
2 |
-10.7733 |
0.0187 |
-2.12 |
0.0336 |
|
3 |
-1.0953 |
0.4525 |
-0.77 |
0.3787 |
|
4 |
-0.4935 |
0.5672 |
-0.51 |
0.4905 |
Single Mean |
1 |
-157.578 |
0.0001 |
-8.26 |
0.0001 |
|
2 |
216.4850 |
0.9999 |
-8.91 |
0.0001 |
|
3 |
-33.0310 |
0.0004 |
-3.03 |
0.0387 |
|
4 |
-14.4477 |
0.0321 |
-2.12 |
0.2388 |
Trend |
1 |
-166.277 |
0.0001 |
-8.48 |
<.0001 |
|
2 |
181.8394 |
0.9999 |
-10.19 |
<.0001 |
|
3 |
-77.2359 |
<.0001 |
-4.01 |
0.0148 |
|
4 |
-41.7384 |
<.0001 |
-3.37 |
0.0680 |
Appendix 2: VAR (2)
Estimation Method: Least Squares Estimation
Seasonal Constant Estimates |
Variable |
Constant |
Season 1 |
Season 2 |
Season 3 |
dlwpi |
0.01394 |
-0.01258 |
-0.01463 |
-0.00450 |
dliip |
0.04654 |
-0.00519 |
0.00039 |
-0.13780 |
dlm1 |
0.01144 |
0.03351 |
0.05328 |
0.00301 |
Model Parameter Estimates |
Equation |
Parameter |
Estimate |
Standard Error |
t Value |
Pr > |t| |
Variable |
dlwpi |
CONST1 |
0.00158 |
0.00961 |
0.16 |
0.8698 |
1 |
|
SD_1_1 |
0.00144 |
0.01299 |
0.11 |
0.9124 |
S_1t |
|
SD_1_2 |
-0.00197 |
0.01170 |
-0.17 |
0.8671 |
S_2t |
|
SD_1_3 |
0.00613 |
0.01194 |
0.51 |
0.6096 |
S_3t |
|
AR1_1_1 |
0.22639 |
0.10926 |
2.07 |
0.0426 |
dlwpi(t-1) |
|
AR1_1_2 |
0.05563 |
0.08592 |
0.65 |
0.5199 |
dliip(t-1) |
|
AR1_1_3 |
0.08854 |
0.06744 |
1.31 |
0.1943 |
dlm1(t-1) |
|
AR2_1_1 |
-0.16897 |
0.09405 |
-1.80 |
0.0775 |
dlwpi(t-2) |
|
AR2_1_2 |
0.05573 |
0.07045 |
0.79 |
0.4321 |
dliip(t-2) |
|
AR2_1_3 |
0.11449 |
0.05616 |
2.04 |
0.0460 |
dlm1(t-2) |
dliip |
CONST2 |
0.02409 |
0.01212 |
1.99 |
0.0515 |
1 |
|
SD_2_1 |
0.00772 |
0.01653 |
0.47 |
0.6422 |
S_1t |
|
SD_2_2 |
0.03394 |
0.01469 |
2.31 |
0.0244 |
S_2t |
|
SD_2_3 |
-0.09845 |
0.01499 |
-6.57 |
0.0001 |
S_3t |
|
AR1_2_1 |
-0.41799 |
0.13353 |
-3.13 |
0.0027 |
dlwpi(t-1) |
|
AR1_2_2 |
0.20349 |
0.10809 |
1.88 |
0.0647 |
dliip(t-1) |
|
AR1_2_3 |
0.13000 |
0.08384 |
1.55 |
0.1264 |
dlm1(t-1) |
|
AR2_2_1 |
-0.00292 |
0.11195 |
-0.03 |
0.9793 |
dlwpi(t-2) |
|
AR2_2_2 |
-0.06808 |
0.09121 |
-0.75 |
0.4584 |
dliip(t-2) |
|
AR2_2_3 |
0.15537 |
0.06984 |
2.22 |
0.0299 |
dlm1(t-2) |
dlm1 |
CONST3 |
0.00490 |
0.01588 |
0.31 |
0.7589 |
1 |
|
SD_3_1 |
0.03024 |
0.02122 |
1.42 |
0.1595 |
S_1t |
|
SD_3_2 |
0.05074 |
0.01916 |
2.65 |
0.0104 |
S_2t |
|
SD_3_3 |
0.05399 |
0.01948 |
2.77 |
0.0075 |
S_3t |
|
AR1_3_1 |
-0.17080 |
0.17574 |
-0.97 |
0.3351 |
dlwpi(t-1) |
|
AR1_3_2 |
0.07945 |
0.14032 |
0.57 |
0.5734 |
dliip(t-1) |
|
AR1_3_3 |
-0.27610 |
0.11252 |
-2.45 |
0.0171 |
dlm1(t-1) |
|
AR2_3_1 |
-0.06520 |
0.14718 |
-0.44 |
0.6594 |
dlwpi(t-2) |
|
AR2_3_2 |
-0.14172 |
0.11526 |
1.23 |
0.2237 |
dliip(t-2) |
|
AR2_3_3 |
0.11877 |
0.09635 |
1.23 |
0.2226 |
dlm1(t-2) |
Schematic Representation of Cross Correlations of Residuals |
Variable/ |
|
|
|
|
|
|
|
|
|
|
|
|
|
Lag |
0 |
1 |
2 |
3 |
4 |
5 |
6 |
7 |
8 |
9 |
10 |
11 |
12 |
dlwpi |
+.. |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
dliip |
.+. |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
dlm1 |
..+ |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
|
+ is > 2*std error, - is < -2*std error, . is between |
Portmanteau Test for Cross Correlations of Residuals |
Up to Lag |
DF |
Chi-Square |
Pr > ChiSq |
3 |
9 |
18.81 |
0.0269 |
4 |
18 |
23.92 |
0.1576 |
5 |
27 |
30.92 |
0.2743 |
6 |
36 |
44.60 |
0.1540 |
7 |
45 |
50.23 |
0.2738 |
8 |
54 |
64.52 |
0.1547 |
9 |
63 |
72.96 |
0.1832 |
10 |
72 |
78.00 |
0.2940 |
11 |
81 |
87.64 |
0.2876 |
12 |
90 |
96.86 |
0.2919 |
Univariate Model ANOVA Diagnostics |
Standard |
Variable |
R-Square |
Deviation |
F Value |
Pr > F |
dlwpi |
0.4808 |
0.00914 |
4.01 |
0.0011 |
dliip |
0.9561 |
0.01752 |
94.43 |
<.0001 |
dlm1 |
0.7564 |
0.02028 |
13.46 |
<.0001 |
Univariate Model White Noise Diagnostics |
|
Durbin |
Normality |
ARCH |
Variable |
Watson |
Chi-Square |
Pr > ChiSq |
F Value |
Pr > F |
dlwpi |
2.04045 |
7.33 |
0.0256 |
0.92 |
0.3413 |
dliip |
2.18189 |
1.19 |
0.5502 |
1.01 |
0.3208 |
dlm1 |
1.99207 |
0.83 |
0.6607 |
0.11 |
0.7423 |
Appendix 3: Percentage Root Mean Square Error (PRMSE)
for WPI based on different combination of lambda and theta |
theta |
|
lambda |
|
1 |
0.9 |
0.8 |
0.7 |
0.6 |
0.5 |
0.4 |
0.3 |
0.2 |
0.1 |
0.9 |
1.4796 |
1.4770 |
1.4736 |
1.4691 |
1.4633 |
1.4560 |
1.4474 |
1.4400 |
1.4446 |
1.4897 |
0.8 |
1.4772 |
1.4741 |
1.4704 |
1.4656 |
1.4597 |
1.4525 |
1.4450 |
1.4407 |
1.4510 |
1.4990 |
0.7 |
1.4739 |
1.4705 |
1.4666 |
1.4615 |
1.4555 |
1.4491 |
1.4435 |
1.4434 |
1.4603 |
1.5091 |
0.6 |
1.4697 |
1.4660 |
1.4617 |
1.4566 |
1.4514 |
1.4465 |
1.4442 |
1.4497 |
1.4732 |
1.5195 |
0.5 |
1.4640 |
1.4603 |
1.4561 |
1.4518 |
1.4481 |
1.4462 |
1.4489 |
1.4611 |
1.4900 |
1.5300 |
0.4 |
1.4571 |
1.4540 |
1.4510 |
1.4488 |
1.4484 |
1.4515 |
1.4607 |
1.4799 |
1.5108 |
1.5399 |
0.3 |
1.4511 |
1.4501 |
1.4503 |
1.4526 |
1.4580 |
1.4681 |
1.4844 |
1.5078 |
1.5345 |
1.5486 |
0.2 |
1.4562 |
1.4607 |
1.4672 |
1.4765 |
1.4890 |
1.5051 |
1.5239 |
1.5434 |
1.5578 |
1.5555 |
0.1 |
1.5099 |
1.5199 |
1.5307 |
1.5419 |
1.5532 |
1.5637 |
1.5725 |
1.5775 |
1.5756 |
1.5599 |
Appendix 4: BVAR(2)
Estimation Method |
Maximum Likelihood Estimation |
Prior Lambda |
0.3 |
Prior Theta |
0.9 |
Seasonal Constant Estimates |
Variable |
Constant |
Season 1 |
Season 2 |
Season 3 |
dlwpi |
0.01506 |
-0.01268 |
-0.01328 |
-0.00170 |
dliip |
0.04363 |
0.02134 |
0.00649 |
-0.13811 |
dlm1 |
0.00979 |
0.02926 |
0.06049 |
0.01558 |
Model Parameter Estimates |
Equation |
Parameter |
Estimate |
Standard Error |
t Value |
Pr > |t| |
Variable |
dlwpi |
CONST1 |
-0.01287 |
0.01307 |
-0.98 |
0.3295 |
1 |
|
SD_1_1 |
0.01495 |
0.01824 |
0.82 |
0.4162 |
S_1t |
|
SD_1_2 |
0.01601 |
0.01596 |
1.00 |
0.3209 |
S_2t |
|
SD_1_3 |
0.01869 |
0.01541 |
1.21 |
0.2308 |
S_3t |
|
AR1_1_1 |
0.27226 |
0.13315 |
2.04 |
0.0463 |
dlwpi(t-1) |
|
AR1_1_2 |
-0.01495 |
0.10841 |
-0.14 |
0.8909 |
dliip(t-1) |
|
AR1_1_3 |
0.13876 |
0.08431 |
1.65 |
0.1062 |
dlm1(t-1) |
|
AR2_1_1 |
-0.31337 |
0.13668 |
-2.29 |
0.0262 |
dlwpi(t-2) |
|
AR2_1_2 |
0.08893 |
0.10384 |
0.86 |
0.3959 |
dliip(t-2) |
|
AR2_1_3 |
0.21975 |
0.08622 |
2.55 |
0.0140 |
dlm1(t-2) |
dliip |
CONST2 |
0.01950 |
0.01624 |
1.20 |
0.2357 |
1 |
|
SD_2_1 |
0.00006 |
0.02267 |
0.00 |
0.9980 |
S_1t |
|
SD_2_2 |
0.03717 |
0.01984 |
1.87 |
0.0669 |
S_2t |
|
SD_2_3 |
-0.10122 |
0.01915 |
-5.29 |
0.0001 |
S_3t |
|
AR1_2_1 |
-0.53137 |
0.16548 |
-3.21 |
0.0023 |
dlwpi(t-1) |
|
AR1_2_2 |
0.21896 |
0.13473 |
1.63 |
0.1106 |
dliip(t-1) |
|
AR1_2_3 |
0.21129 |
0.10478 |
2.02 |
0.0492 |
dlm1(t-1) |
|
AR2_2_1 |
0.03900 |
0.16987 |
0.23 |
0.8194 |
dlwpi(t-2) |
|
AR2_2_2 |
-0.14044 |
0.12905 |
-1.09 |
0.2818 |
dliip(t-2) |
|
AR2_2_3 |
0.31351 |
0.10715 |
2.93 |
0.0052 |
dlm1(t-2) |
dlm1 |
CONST3 |
-0.00311 |
0.02139 |
-0.15 |
0.8850 |
1 |
|
SD_3_1 |
0.04310 |
0.02985 |
1.44 |
0.1552 |
S_1t |
|
SD_3_2 |
0.06106 |
0.02612 |
2.34 |
0.0235 |
S_2t |
|
SD_3_3 |
0.05923 |
0.02522 |
2.35 |
0.0229 |
S_3t |
|
AR1_3_1 |
-0.21334 |
0.21793 |
-0.98 |
0.3324 |
dlwpi(t-1) |
|
AR1_3_2 |
0.05611 |
0.17744 |
0.32 |
0.7532 |
dliip(t-1) |
|
AR1_3_3 |
-0.29889 |
0.13799 |
-2.17 |
0.0352 |
dlm1(t-1) |
|
AR2_3_1 |
-0.14122 |
0.22371 |
-0.63 |
0.5308 |
dlwpi(t-2) |
|
AR2_3_2 |
0.24353 |
0.16995 |
1.43 |
0.1582 |
dliip(t-2) |
|
AR2_3_3 |
0.17355 |
0.14112 |
1.23 |
0.2246 |
dlm1(t-2) |
Schematic Representation of Cross
Correlations of Residuals Variable |
Lag |
0 |
1 |
2 |
3 |
4 |
5 |
6 |
7 |
8 |
9 |
10 |
11 |
12 |
dlwpi |
+.. |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
... |
dliip |
.+. |
|
|
|
|
|
|
|
|
|
|
|
|
dlm1 |
..+ |
|
|
|
|
|
|
|
|
|
|
|
|
+ is > 2*std error, - is < -2*std error, . is between |
Portmanteau Test for Cross Correlations of Residuals |
Up to Lag |
DF |
Chi-Square |
Pr > ChiSq |
3 |
9 |
18.36 |
0.0312 |
4 |
18 |
22.65 |
0.2045 |
5 |
27 |
29.51 |
0.3366 |
6 |
36 |
43.71 |
0.1766 |
7 |
45 |
49.10 |
0.3123 |
8 |
54 |
62.21 |
0.2071 |
9 |
63 |
68.45 |
0.2976 |
10 |
72 |
73.81 |
0.4188 |
11 |
81 |
82.72 |
0.4259 |
12 |
90 |
91.71 |
0.4301 |
Univariate Model ANOVA Diagnostics |
Variable |
R-Square |
Std. Deviation |
F Value |
Pr > F |
dlwpi |
0.4768 |
0.00818 |
3.95 |
0.0012 |
dliip |
0.9542 |
0.01596 |
90.31 |
<.0001 |
dlm1 |
0.7499 |
0.01833 |
12.99 |
<.0001 |
Univariate Model White Noise Diagnostics |
|
|
Normality |
ARCH |
Variable |
Durbin Watson |
Chi-Square |
Pr > ChiSq |
F Value |
Pr > F |
dlwpi |
2.10694 |
6.85 |
0.0326 |
0.56 |
0.4564 |
dliip |
1.99104 |
0.17 |
0.9202 |
0.84 |
0.3647 |
dlm1 |
2.02638 |
0.99 |
0.6106 |
0.14 |
0.7105 |
* Authors are working as Research Officers in the Department of Statistics and
Information Management, Reserve Bank of India. The views expressed in the paper
are those of authors and do not necessarily represent those of the RBI. Erros and
omissions, if any,are the sole responsibility of the authors.
Select References
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Helmut Lütkepohl, 2006, “ New Introduction to Multiple Time Series Analysis”.
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Quarterly Review.
Litterman, Robert B. 1984b. “Specifying Vector Autoregressions for
Macroeconomic Forecasting”. Federal Reserve Bank of Minneapolis Staff
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