Презентация Financial econometrics онлайн

Содержание слайда: Financial Econometrics Dr. Kashif Saleem Associate Professor (Finance) University of Wollongong in Dubai

Содержание слайда: Univariate time series models Univariate time series modelling Moving average processes Autoregressive processes ARMA processes ARIMA process Exponential Smoothing Forecasting in Econometrics Vector Autoregressive Models

Содержание слайда: Moving Average Processes Let ut (t=1,2,3,...) be a sequence of independently and identically distributed (iid) random variables with E(ut)=0 and Var(ut)= , then yt =  + ut + 1ut-1 + 2ut-2 + ... + qut-q is a qth order moving average model MA(q). Its properties are E(yt)=; Var(yt) = 0 = (1+ )2 Covariances

Содержание слайда: Autoregressive Processes An autoregressive model of order p, an AR(p) can be expressed as Or using the lag operator notation: Lyt = yt-1 Liyt = yt-i or or where .  

Содержание слайда: ARMA Processes By combining the AR(p) and MA(q) models, we can obtain an ARMA(p,q) model: where and or with

Содержание слайда: Summary of the Behaviour of the acf for AR and MA Processes An autoregressive process has a geometrically decaying acf number of non zero points of pacf = AR order   A moving average process has Number of non zero points of acf = MA order a geometrically decaying pacf

Содержание слайда: Some sample acf and pacf plots for standard processes The acf and pacf are not produced analytically from the relevant formulae for a model of that type, but rather are estimated using 100,000 simulated observations with disturbances drawn from a normal distribution. ACF and PACF for an MA(1) Model: yt = – 0.5ut-1 + ut

Содержание слайда: ACF and PACF for an MA(2) Model: yt = 0.5ut-1 - 0.25ut-2 + ut

Содержание слайда: ACF and PACF for a slowly decaying AR(1) Model: yt = 0.9yt-1 + ut

Содержание слайда: ACF and PACF for a more rapidly decaying AR(1) Model: yt = 0.5yt-1 + ut

Содержание слайда: ACF and PACF for a more rapidly decaying AR(1) Model with Negative Coefficient: yt = -0.5yt-1 + ut

Содержание слайда: ACF and PACF for a Non-stationary Model (i.e. a unit coefficient): yt = yt-1 + ut

Содержание слайда: ACF and PACF for an ARMA(1,1): yt = 0.5yt-1 + 0.5ut-1 + ut

Содержание слайда: Building ARMA Models - The Box Jenkins Approach Box and Jenkins (1970) were the first to approach the task of estimating an ARMA model in a systematic manner. There are 3 steps to their approach: 1. Identification 2. Estimation 3. Model diagnostic checking   Step 1: - Involves determining the order of the model. - Use of graphical procedures - A better procedure is now available  

Содержание слайда: Building ARMA Models - The Box Jenkins Approach (cont’d) Step 2: - Estimation of the parameters - Can be done using least squares or maximum likelihood depending on the model. Step 3: - Model checking Box and Jenkins suggest 2 methods: - deliberate overfitting –step 1 sugest lag2 – but we use lag 5 - residual diagnostics --- acf, pacf, LB test, etc.

Содержание слайда: Some More Recent Developments in ARMA Modelling Identification would typically not be done using acf’s. using information criteria, which embody 2 factors - a term which is a function of the RSS - some penalty for adding extra parameters The object is to choose the number of parameters which minimises the information criterion.

Содержание слайда: Information Criteria for Model Selection  The three most popular criteria are Akaike’s (1974) information criterion (AIC), Schwarz’s (1978) Bayesian information criterion (SBIC), and the Hannan-Quinn criterion (HQIC).     where k = p + q + 1, T = sample size. So we min. IC s.t.   SBIC embodies a stiffer penalty term than AIC. Which IC should be preferred if they suggest different model orders? SBIC is strongly consistent but (inefficient). AIC is not consistent, and will typically pick “bigger” models.

Содержание слайда: ARIMA Models As distinct from ARMA models. The I stands for integrated. An integrated autoregressive process is one with a characteristic root on the unit circle. Typically researchers difference the variable as necessary and then build an ARMA model on those differenced variables. An ARMA(p,q) model in the variable differenced d times is equivalent to an ARIMA(p,d,q) model on the original data.

Содержание слайда: Exponential Smoothing Another modelling and forecasting technique   How much weight do we attach to previous observations?   Expect recent observations to have the most power in helping to forecast future values of a series.   The equation for the model St =  yt + (1-)St-1 (1) where  is the smoothing constant, with 01 yt is the current realised value St is the current smoothed value

Содержание слайда: Forecasting in Econometrics Forecasting = prediction. An important test of the adequacy of a model. We can distinguish two approaches: - Econometric (structural) forecasting - Time series forecasting To understand how to construct forecasts, we need the idea of conditional expectations: E(yt+1  t ) We cannot forecast a white noise process: E(ut+s  t ) = 0  s > 0.

Содержание слайда: In-Sample Versus Out-of-Sample Expect the “forecast” of the model to be good in-sample.   Say we have some data - e.g. monthly FTSE returns for 120 months: 1990M1 – 1999M12. We could use all of it to build the model, or keep some observations back:       A good test of the model since we have not used the information from 1999M1 onwards when we estimated the model parameters.

Содержание слайда: Models for Forecasting Time Series Models The current value of a series, yt, is modelled as a function only of its previous values and the current value of an error term (and possibly previous values of the error term). Models include: simple unweighted averages exponentially weighted averages ARIMA models Non-linear models – e.g. threshold models, GARCH, bilinear models, etc.

Содержание слайда: Forecasting with MA Models An MA(q) only has memory of q.   e.g. say we have estimated an MA(3) model:   yt =  + 1ut-1 +  2ut-2 +  3ut-3 + ut yt+1 =  +  1ut +  2ut-1 +  3ut-2 + ut+1 yt+2 =  +  1ut+1 +  2ut +  3ut-1 + ut+2 yt+3 =  +  1ut+2 +  2ut+1 +  3ut + ut+3   We are at time t and we want to forecast 1,2,..., s steps ahead.   We know yt , yt-1, ..., and ut , ut-1….  

Содержание слайда: Forecasting with MA Models (cont’d) ft, 1 = E(yt+1  t ) = E( +  1ut +  2ut-1 +  3ut-2 + ut+1) =  +  1ut +  2ut-1 +  3ut-2   ft, 2 = E(yt+2  t ) = E( +  1ut+1 +  2ut +  3ut-1 + ut+2) =  +  2ut +  3ut-1   ft, 3 = E(yt+3  t ) = E( +  1ut+2 +  2ut+1 +  3ut + ut+3) =  +  3ut   ft, 4 = E(yt+4  t ) =    ft, s = E(yt+s  t ) =   s  4  

Содержание слайда: Forecasting with AR Models Say we have estimated an AR(2)   yt =  + 1yt-1 +  2yt-2 + ut yt+1 =  +  1yt +  2yt-1 + ut+1 yt+2 =  +  1yt+1 +  2yt + ut+2 yt+3 =  +  1yt+2 +  2yt+1 + ut+3   ft, 1 = E(yt+1  t ) = E( +  1yt +  2yt-1 + ut+1) =  +  1E(yt) +  2E(yt-1) =  +  1yt +  2yt-1   ft, 2 = E(yt+2  t ) = E( +  1yt+1 +  2yt + ut+2) =  +  1E(yt+1) +  2E(yt) =  +  1 ft, 1 +  2yt  

Содержание слайда: Forecasting with AR Models (cont’d) ft, 3 = E(yt+3  t ) = E( +  1yt+2 +  2yt+1 + ut+3) =  +  1E(yt+2) +  2E(yt+1) =  +  1 ft, 2 +  2 ft, 1   We can see immediately that   ft, 4 =  +  1 ft, 3 +  2 ft, 2 etc., so   ft, s =  +  1 ft, s-1 +  2 ft, s-2   Can easily generate ARMA(p,q) forecasts in the same way.

Содержание слайда: How can we test whether a forecast is accurate or not? Some of the most popular criteria for assessing the accuracy of time series forecasting techniques are: Mean square error: MAE is given by:   Mean absolute percentage error: Theil’s U-statistic :

Содержание слайда: Vector Autoregressive Models A natural generalisation of autoregressive models popularised by Sims A VAR is in a sense a systems regression model i.e. there is more than one dependent variable.   Simplest case is a bivariate VAR where uit is an iid disturbance term with E(uit)=0, i=1,2; E(u1t u2t)=0.   The analysis could be extended to a VAR(g) model, or so that there are g variables and g equations.

Содержание слайда: Vector Autoregressive Models: Notation and Concepts One important feature of VARs is the compactness with which we can write the notation. For example, consider the case from above where k=1.   We can write this as   or     or even more compactly as   yt = 0 + 1 yt-1 + ut g1 g1 gg g1 g1

Содержание слайда: Vector Autoregressive Models: Notation and Concepts (cont’d) This model can be extended to the case where there are k lags of each variable in each equation: yt = 0 + 1 yt-1 + 2 yt-2 +...+ k yt-k + ut g1 g1 gg g1 gg g1 gg g1 g1 We can also extend this to the case where the model includes first difference terms and cointegrating relationships (a VECM).

Содержание слайда: Vector Autoregressive Models Compared with Structural Equations Models Advantages of VAR Modelling - Do not need to specify which variables are endogenous or exogenous - all are endogenous - Allows the value of a variable to depend on more than just its own lags or combinations of white noise terms, so more general than ARMA modelling - Provided that there are no contemporaneous terms on the right hand side of the equations, can simply use OLS separately on each equation - Forecasts are often better than “traditional structural” models. Problems with VAR’s - VAR’s are a-theoretical (as are ARMA models) - How do you decide the appropriate lag length? - So many parameters! If we have g equations for g variables and we have k lags of each of the variables in each equation, we have to estimate (g+kg2) parameters. e.g. g=3, k=3, parameters = 30 - How do we interpret the coefficients?

Содержание слайда: Choosing the Optimal Lag Length for a VAR 2 possible approaches: cross-equation restrictions and information criteria Cross-Equation Restrictions In the spirit of (unrestricted) VAR modelling, each equation should have the same lag length Suppose that a bivariate VAR(8) estimated using quarterly data has 8 lags of the two variables in each equation, and we want to examine a restriction that the coefficients on lags 5 through 8 are jointly zero. This can be done using a likelihood ratio test Denote the variance-covariance matrix of residuals (given by /T), as . The likelihood ratio test for this joint hypothesis is given by

Содержание слайда: Choosing the Optimal Lag Length for a VAR (cont’d) where is the variance-covariance matrix of the residuals for the restricted model (with 4 lags), is the variance-covariance matrix of residuals for the unrestricted VAR (with 8 lags), and T is the sample size. The test statistic is asymptotically distributed as a 2 with degrees of freedom equal to the total number of restrictions. In the VAR case above, we are restricting 4 lags of two variables in each of the two equations = a total of 4 * 2 * 2 = 16 restrictions. In the general case where we have a VAR with p equations, and we want to impose the restriction that the last q lags have zero coefficients, there would be p2q restrictions altogether Disadvantages: Conducting the LR test is cumbersome and requires a normality assumption for the disturbances.

Содержание слайда: Information Criteria for VAR Lag Length Selection Multivariate versions of the information criteria are required. These can be defined as: where all notation is as above and k is the total number of regressors in all equations, which will be equal to g2k + g for g equations, each with k lags of the g variables, plus a constant term in each equation. The values of the information criteria are constructed for 0, 1, … lags (up to some pre-specified maximum ).

Содержание слайда: Block Significance and Causality Tests It is likely that, when a VAR includes many lags of variables, it will be difficult to see which sets of variables have significant effects on each dependent variable and which do not. For illustration, consider the following bivariate VAR(3): This VAR could be written out to express the individual equations as We might be interested in testing the following hypotheses, and their implied restrictions on the parameter matrices:

Содержание слайда: Block Significance and Causality Tests (cont’d) Each of these four joint hypotheses can be tested within the F-test framework, since each set of restrictions contains only parameters drawn from one equation. These tests could also be referred to as Granger causality tests. Granger causality tests seek to answer questions such as “Do changes in y1 cause changes in y2?” If y1 causes y2, lags of y1 should be significant in the equation for y2. If this is the case, we say that y1 “Granger-causes” y2. If y2 causes y1, lags of y2 should be significant in the equation for y1. If both sets of lags are significant, there is “bi-directional causality”

Содержание слайда: Impulse Responses VAR models are often difficult to interpret: one solution is to construct the impulse responses and variance decompositions. Impulse responses trace out the responsiveness of the dependent variables in the VAR to shocks to the error term. A unit shock is applied to each variable and its effects are noted. Consider for example a simple bivariate VAR(1): A change in u1t will immediately change y1. It will change change y2 and also y1 during the next period. We can examine how long and to what degree a shock to a given equation has on all of the variables in the system.

Содержание слайда: Variance Decompositions Variance decompositions offer a slightly different method of examining VAR dynamics. They give the proportion of the movements in the dependent variables that are due to their “own” shocks, versus shocks to the other variables. This is done by determining how much of the s-step ahead forecast error variance for each variable is explained innovations to each explanatory variable (s = 1,2,…). The variance decomposition gives information about the relative importance of each shock to the variables in the VAR.

Содержание слайда: Home Assignment Vector Autoregressive Model: Run a VAR (3) model by using exchange rate data on any 3 series Conduct Block Significance and Causality Tests on your model Present graphically Impulse Responses Present graphically Variance Decompositions Interpret your results

Содержание слайда: Home Assignment ARMA FAMILY MODELS: Use MICEX data to run the following models both on level and log return data performing Stationarity and Unit Root Testing MA (5) AR (5) ARMA (5,5) ARMA (P,Q) – Based on the AIC Code Interpret your results