Cointegration and Implications for Forecasting
|
|
- Noah Paul Shelton
- 5 years ago
- Views:
Transcription
1 Coinegraion and Implicaions for Forecasing
2 Two examples (A) Y Y (B) Y Example B: Coinegraion Y and coinegraed wih coinegraing vecor [1, 0.9] because Y is a saionary process even hough Y and Example A: No such ha Y are I(1) is saionary
3 Behaviour of OLS behaves very differenly depending on siuaion A or B [A] Spurious Regression Y Y Simulaed -saisics in regression of Y on, 1000 replicaions
4 Comparison wih saionary case Disribuion on righ: simulaed -sas when and Y are saionary AR(1)
5 Siuaion is worse wih random walks wih drif Y Y Simulaed -saisics in regression of Y on, 1000 replicaions A c y n e u q re F
6 1 Y Y
7 [B] In Coinegraed Case: Superconsisency Y Y Simulaed -Saisics
8 Y Y Simulaed Sandard Errors
9 Summary: OLS behaves differenly when variables are saionary / no-saionary In non-saionary case: we saw Y Y 1 1 Y ~~ Spurious Regressions: huge -sas! ~~ Superconsisency: huge -sas! Phenomenon is second example is called Coinegraion Y and coinegraed wih coinegraing vecor [1, 0.9] because Y is saionary even hough Y and are I(1) Firs example no such ha Y is saionary
10 Example funcions of he form Early macro-economeric work, common o esimae consumpion C Y 0 1 Using Singapore daa from 1975Q1 o 2011Q2 (we use logs of he variables hroughou), we ge he regression All seems good Cˆ (0.059)(0.006) Y The propensiy o consume is beween zero and one as expeced. The -saisic on 1 ˆ is , 2 R is bu is his regression spurious? if no, how o use coinegraing relaionship for forecasing? if yes, does i mean a log(cons) canno be used o forecas log(gdp)
11 L O G (C O N S ) L O G (G D P ) S N O C L LGDP
12 Tesing for Coinegraion [Engle-Granger] Check if he residual series from regression is I (1) a. Regress Y 0 1 by OLS b.tes ˆ for uni roo using ADF: collec residuals ˆ Y ()ˆ ˆ 0 1 ˆ ˆ ˆ... ˆ u p1 p1 If 0 - uni roo in - and Y no coinegraed If 0 - hen no uni roo in - and Y coinegraed Imporan: usual Dickey-Fuller criical values do no apply, because we are esing on he residuals, no he acual noise erms
13 Mos economeric sofware packages include he appropriae criical values, which have been obained using simulaion mehods. Example Tes for coinegraing relaionship beween log( RGDP _) SG and Composie Leading Index CLI for Singapore. L O G (R G D P _ S G ) C L I
14 We begin by regressing log(rgdp_sg) on CLI: Dependen Variable: LOG(RGDP_SG) Mehod: Leas Squares Sample: 1981Q1 2011Q4 Included observaions: 124 Variable Coefficien Sd. Error -Saisic Prob. C CLI R-sqr Mean dependen var Adj R-sqr S.D. dependen var S.E. of reg Akaike info crierion Sum sqrd resid Schwarz crierion Log likelihood Hannan-Quinn crier F-saisic Durbin-Wason sa Prob(F-sa) Residual Acual Fied
15 The Engle-Granger es resuls are: Coinegraion Tes - Engle-Granger Specificaion: LOG(RGDP_SG) CLI C Auomaic lag specificaion (lag=1 based on Schwarz Info Crierion, maxlag=12) Value Prob.* Engle-Granger au-sa *MacKinnon (1996) p-values. Engle-Granger Tes Equaion: Variable Coefficien Sd. Error -Saisic Prob. RESID(-1) D(RESID(-1)) The eviews commands are: smpl 1981q1 2004q4 equaion eq1.coinreg log(rgdp_sg) c cli eq1.coin(mehod=eg) The -saisic on he esimaed ˆ has p-value Rejec null ha he wo series are no coinegraed
16 Example: log( RGDP _) SG and log()nod Dependen Variable: LOG(RGDP_SG) Mehod: Leas Squares Sample: 1981Q1 2011Q4 Included obss: 124 Variable Coef. Sd. Error -Sa. Prob. C LOG(NOD) R-squared Mean dep. var Adj R-sqr S.D. dep var S.E. of reg Akaike info crierion Sum sqr resid Schwarz crierion Log likelihood H-Q crierion F-saisic Durbin-Wason sa Prob(F-saisic) Residual Acual Fied Coinegraion Tes - Engle-Granger Specificaion: LOG(RGDP_SG) LOG(NOD) C Auo lag specificaion (lag=0 based on SIC) Value Prob.* Engle-Granger au-saisic *MacKinnon (1996) p-values. Engle-Granger Tes Equaion: Variable Coefficien Sd. Error -Sa Prob. RESID(-1) We do no rejec he null ha here is no coinegraing relaionship beween he wo variables.
17 8.3 Implicaion for Forecasing -- he Error Correcion Form If Y and are coinegraed, hen here exiss an error correcion form: Y Y () Y Inuiion: if Y 0 1 holds in he long run, hen fuure changes in Y mus end oward Y 0 1 Change in Y should reac o pas deviaions
18 Example Suppose Y u, u ~(0) I u, u ~(0) I Subracing boh sides by Y 1 and making a subsiuion for gives Rearranging: Y Y () u Y u y Y Y u u ()() This is a simple error-correcion form for no lags of 1 Y or Y
19 In his sysem When here is a posiive error ( Y ) hen Y () Y y ends o be negaive Y ends o fall owards he coinegraing relaionship When here is a negaive error ( Y ) hen Y () Y y ends o be posiive Y rises owards he coinegraing relaionship Noe he implicaion of he error-correcion form for forecasing: - pas errors in he coinegraing relaionship helps o predic fuure changes in Y because of a endency o rever o he coinegraing relaionship
20 Remarks Because 1 here, he correcion is on average of he full amoun In general, he adjusmen facor need no be 1, i.e., he immediae response migh no be a correcion of he full amoun. Correcion migh ake place slowly. In general, here will be an error-correcion form for boh possible, however, ha only Y responds, or only Y and responds., hough i is
21 Example The following is a Vecor Auoregression of order 1 Y 0.9Y y 0.3Y x i.e., Y Y 1 y, x, In his example, boh Y and are I(1) (proof omied) They are also coinegraed wih coinegraing vecor [1, 1], i.e., Y is I(0) To see his, subracing he second equaion from he firs: Y 0.6Y y x () Y 0.6()() Y 1 1 y x
22 Noe ha Y Y 1 y, x, Y Y 1 Y 1 y, x, Y Y Y 1 y, x, ζ Y 1 y, x, α β 0.1 () y, Y x, y, x, The wo equaions are herefore Y 0.1() Y 1 1 y 0.3() Y 1 1 x
23 These equaions show ha - boh Y and have error-correcion forms, and boh adjus - If a ime 1 here is posiive error, i.e., Y 1 1, hen Y decreases ( Y 0) and increases ( 0) o move he variables back owards he relaionship Y - The adjusmen facors are 0.1 in α - The vecor β gives he coinegraing vecor and 0.3 are called he adjusmen facors, given - Noice ha he marix ζ 0 was wrien as he ouer produc of he vecor of adjusmen facors and he coinegraing vecor - The VAR ransformed ino equaions involving Y (and is lags) and Y 1 he vecor error-correcion form is called
24 Warning: i is emping o hink ha if wo variables are no coinegraed, hen here is no connecion beween he wo. However, here may sill be a relaionship beween and, even if Y and are I (1), bu no coinegraed. Y In paricular, here may sill be a relaionship of he form Y Y y perhaps wih more lags of he firs differences of Y and
25 Example We build an Error Correcion Model for log( RGDP _) SG using is coinegraing relaionship wih CLI esimaed earlier log( RGDP _) SG CLI The error correcion represenaion is hen of he form d(log( RGDP _)) SG d(log( RGDP _))() SG... d CLI (log( RGDP _) SG ) CLI wih possibly more lags of d(log( RGDP _)) SG and d() CLI 1 1
26 We begin by regressing d(log( RGDP _)) SG on he error correcion erm only, using he command ls d(log(rgdp_sg)) c (log(rgdp_sg(-1)) *cli(-1) ) and add lags of firs differences, seasonals, ec. We sele on he error-correcion form wih one lag of d() CLI and seasonals equaion eq3.ls d(log(rgdp_sg)) c @seas(4) d(cli(-1))
27 Dependen Variable: D(LOG(RGDP_SG)) Sample: 1980Q1 2004Q4 Included observaions: 100 Variable CoefficienSd. Error-Saisic Prob. C LOG(Y(-1)) *CLI(-1) D(CLI(-1)) Incidenally, he 2 R for his regression is
28 We can forecas from his regression in he usual way: smpl 2005q1 2011q4 eq3.fi(f=na) y_f y_se D(LOG(Y)) Y_UP Y_F Y_DOWN The forecas 2 R is jus over 0.15
29 We can incorporae lag BIZEP ino his model equaion eq3.ls d(log(rgdp_sg)) c @seas(4) d(cli(-1)) bizexp(-1) Y Y_F Y_UP Y_DOWN This model generaes a slighly higher forecas-r of
Modeling and Forecasting Volatility Autoregressive Conditional Heteroskedasticity Models. Economic Forecasting Anthony Tay Slide 1
Modeling and Forecasing Volailiy Auoregressive Condiional Heeroskedasiciy Models Anhony Tay Slide 1 smpl @all line(m) sii dl_sii S TII D L _ S TII 4,000. 3,000.1.0,000 -.1 1,000 -. 0 86 88 90 9 94 96 98
More informationLecture 5. Time series: ECM. Bernardina Algieri Department Economics, Statistics and Finance
Lecure 5 Time series: ECM Bernardina Algieri Deparmen Economics, Saisics and Finance Conens Time Series Modelling Coinegraion Error Correcion Model Two Seps, Engle-Granger procedure Error Correcion Model
More informationLicenciatura de ADE y Licenciatura conjunta Derecho y ADE. Hoja de ejercicios 2 PARTE A
Licenciaura de ADE y Licenciaura conjuna Derecho y ADE Hoja de ejercicios PARTE A 1. Consider he following models Δy = 0.8 + ε (1 + 0.8L) Δ 1 y = ε where ε and ε are independen whie noise processes. In
More informationUnit Root Time Series. Univariate random walk
Uni Roo ime Series Univariae random walk Consider he regression y y where ~ iid N 0, he leas squares esimae of is: ˆ yy y y yy Now wha if = If y y hen le y 0 =0 so ha y j j If ~ iid N 0, hen y ~ N 0, he
More informationTime series Decomposition method
Time series Decomposiion mehod A ime series is described using a mulifacor model such as = f (rend, cyclical, seasonal, error) = f (T, C, S, e) Long- Iner-mediaed Seasonal Irregular erm erm effec, effec,
More informationVectorautoregressive Model and Cointegration Analysis. Time Series Analysis Dr. Sevtap Kestel 1
Vecorauoregressive Model and Coinegraion Analysis Par V Time Series Analysis Dr. Sevap Kesel 1 Vecorauoregression Vecor auoregression (VAR) is an economeric model used o capure he evoluion and he inerdependencies
More informationMethodology. -ratios are biased and that the appropriate critical values have to be increased by an amount. that depends on the sample size.
Mehodology. Uni Roo Tess A ime series is inegraed when i has a mean revering propery and a finie variance. I is only emporarily ou of equilibrium and is called saionary in I(0). However a ime series ha
More informationProperties of Autocorrelated Processes Economics 30331
Properies of Auocorrelaed Processes Economics 3033 Bill Evans Fall 05 Suppose we have ime series daa series labeled as where =,,3, T (he final period) Some examples are he dail closing price of he S&500,
More informationR t. C t P t. + u t. C t = αp t + βr t + v t. + β + w t
Exercise 7 C P = α + β R P + u C = αp + βr + v (a) (b) C R = α P R + β + w (c) Assumpions abou he disurbances u, v, w : Classical assumions on he disurbance of one of he equaions, eg. on (b): E(v v s P,
More informationChapter 16. Regression with Time Series Data
Chaper 16 Regression wih Time Series Daa The analysis of ime series daa is of vial ineres o many groups, such as macroeconomiss sudying he behavior of naional and inernaional economies, finance economiss
More informationStationary Time Series
3-Jul-3 Time Series Analysis Assoc. Prof. Dr. Sevap Kesel July 03 Saionary Time Series Sricly saionary process: If he oin dis. of is he same as he oin dis. of ( X,... X n) ( X h,... X nh) Weakly Saionary
More informationNonstationarity-Integrated Models. Time Series Analysis Dr. Sevtap Kestel 1
Nonsaionariy-Inegraed Models Time Series Analysis Dr. Sevap Kesel 1 Diagnosic Checking Residual Analysis: Whie noise. P-P or Q-Q plos of he residuals follow a normal disribuion, he series is called a Gaussian
More informationRegression with Time Series Data
Regression wih Time Series Daa y = β 0 + β 1 x 1 +...+ β k x k + u Serial Correlaion and Heeroskedasiciy Time Series - Serial Correlaion and Heeroskedasiciy 1 Serially Correlaed Errors: Consequences Wih
More informationDistribution of Estimates
Disribuion of Esimaes From Economerics (40) Linear Regression Model Assume (y,x ) is iid and E(x e )0 Esimaion Consisency y α + βx + he esimaes approach he rue values as he sample size increases Esimaion
More informationA Specification Test for Linear Dynamic Stochastic General Equilibrium Models
Journal of Saisical and Economeric Mehods, vol.1, no.2, 2012, 65-70 ISSN: 2241-0384 (prin), 2241-0376 (online) Scienpress Ld, 2012 A Specificaion Tes for Linear Dynamic Sochasic General Equilibrium Models
More informationWisconsin Unemployment Rate Forecast Revisited
Wisconsin Unemploymen Rae Forecas Revisied Forecas in Lecure Wisconsin unemploymen November 06 was 4.% Forecass Poin Forecas 50% Inerval 80% Inerval Forecas Forecas December 06 4.0% (4.0%, 4.0%) (3.95%,
More informationOBJECTIVES OF TIME SERIES ANALYSIS
OBJECTIVES OF TIME SERIES ANALYSIS Undersanding he dynamic or imedependen srucure of he observaions of a single series (univariae analysis) Forecasing of fuure observaions Asceraining he leading, lagging
More informationExercise: Building an Error Correction Model of Private Consumption. Part II Testing for Cointegration 1
Bo Sjo 200--24 Exercise: Building an Error Correcion Model of Privae Consumpion. Par II Tesing for Coinegraion Learning objecives: This lab inroduces esing for he order of inegraion and coinegraion. The
More informationDynamic Econometric Models: Y t = + 0 X t + 1 X t X t k X t-k + e t. A. Autoregressive Model:
Dynamic Economeric Models: A. Auoregressive Model: Y = + 0 X 1 Y -1 + 2 Y -2 + k Y -k + e (Wih lagged dependen variable(s) on he RHS) B. Disribued-lag Model: Y = + 0 X + 1 X -1 + 2 X -2 + + k X -k + e
More informationDistribution of Least Squares
Disribuion of Leas Squares In classic regression, if he errors are iid normal, and independen of he regressors, hen he leas squares esimaes have an exac normal disribuion, no jus asympoic his is no rue
More informationEcon107 Applied Econometrics Topic 7: Multicollinearity (Studenmund, Chapter 8)
I. Definiions and Problems A. Perfec Mulicollineariy Econ7 Applied Economerics Topic 7: Mulicollineariy (Sudenmund, Chaper 8) Definiion: Perfec mulicollineariy exiss in a following K-variable regression
More informationWednesday, November 7 Handout: Heteroskedasticity
Amhers College Deparmen of Economics Economics 360 Fall 202 Wednesday, November 7 Handou: Heeroskedasiciy Preview Review o Regression Model o Sandard Ordinary Leas Squares (OLS) Premises o Esimaion Procedures
More informationLecture 15. Dummy variables, continued
Lecure 15. Dummy variables, coninued Seasonal effecs in ime series Consider relaion beween elecriciy consumpion Y and elecriciy price X. The daa are quarerly ime series. Firs model ln α 1 + α2 Y = ln X
More informationEcon Autocorrelation. Sanjaya DeSilva
Econ 39 - Auocorrelaion Sanjaya DeSilva Ocober 3, 008 1 Definiion Auocorrelaion (or serial correlaion) occurs when he error erm of one observaion is correlaed wih he error erm of any oher observaion. This
More informationSTAD57 Time Series Analysis. Lecture 5
STAD57 Time Series Analysis Lecure 5 1 Exploraory Daa Analysis Check if given TS is saionary: µ is consan σ 2 is consan γ(s,) is funcion of h= s If no, ry o make i saionary using some of he mehods below:
More informationIntroduction D P. r = constant discount rate, g = Gordon Model (1962): constant dividend growth rate.
Inroducion Gordon Model (1962): D P = r g r = consan discoun rae, g = consan dividend growh rae. If raional expecaions of fuure discoun raes and dividend growh vary over ime, so should he D/P raio. Since
More informationDiebold, Chapter 7. Francis X. Diebold, Elements of Forecasting, 4th Edition (Mason, Ohio: Cengage Learning, 2006). Chapter 7. Characterizing Cycles
Diebold, Chaper 7 Francis X. Diebold, Elemens of Forecasing, 4h Ediion (Mason, Ohio: Cengage Learning, 006). Chaper 7. Characerizing Cycles Afer compleing his reading you should be able o: Define covariance
More informationOutline. lse-logo. Outline. Outline. 1 Wald Test. 2 The Likelihood Ratio Test. 3 Lagrange Multiplier Tests
Ouline Ouline Hypohesis Tes wihin he Maximum Likelihood Framework There are hree main frequenis approaches o inference wihin he Maximum Likelihood framework: he Wald es, he Likelihood Raio es and he Lagrange
More informationBias in Conditional and Unconditional Fixed Effects Logit Estimation: a Correction * Tom Coupé
Bias in Condiional and Uncondiional Fixed Effecs Logi Esimaion: a Correcion * Tom Coupé Economics Educaion and Research Consorium, Naional Universiy of Kyiv Mohyla Academy Address: Vul Voloska 10, 04070
More informationACE 562 Fall Lecture 8: The Simple Linear Regression Model: R 2, Reporting the Results and Prediction. by Professor Scott H.
ACE 56 Fall 5 Lecure 8: The Simple Linear Regression Model: R, Reporing he Resuls and Predicion by Professor Sco H. Irwin Required Readings: Griffihs, Hill and Judge. "Explaining Variaion in he Dependen
More informationArima Fit to Nigerian Unemployment Data
2012, TexRoad Publicaion ISSN 2090-4304 Journal of Basic and Applied Scienific Research www.exroad.com Arima Fi o Nigerian Unemploymen Daa Ee Harrison ETUK 1, Barholomew UCHENDU 2, Uyodhu VICTOR-EDEMA
More informationChickens vs. Eggs: Replicating Thurman and Fisher (1988) by Arianto A. Patunru Department of Economics, University of Indonesia 2004
Chicens vs. Eggs: Relicaing Thurman and Fisher (988) by Ariano A. Paunru Dearmen of Economics, Universiy of Indonesia 2004. Inroducion This exercise lays ou he rocedure for esing Granger Causaliy as discussed
More informationFinancial Econometrics Jeffrey R. Russell Midterm Winter 2009 SOLUTIONS
Name SOLUTIONS Financial Economerics Jeffrey R. Russell Miderm Winer 009 SOLUTIONS You have 80 minues o complee he exam. Use can use a calculaor and noes. Try o fi all your work in he space provided. If
More informationReady for euro? Empirical study of the actual monetary policy independence in Poland VECM modelling
Macroeconomerics Handou 2 Ready for euro? Empirical sudy of he acual moneary policy independence in Poland VECM modelling 1. Inroducion This classes are based on: Łukasz Goczek & Dagmara Mycielska, 2013.
More informationChapter 15. Time Series: Descriptive Analyses, Models, and Forecasting
Chaper 15 Time Series: Descripive Analyses, Models, and Forecasing Descripive Analysis: Index Numbers Index Number a number ha measures he change in a variable over ime relaive o he value of he variable
More informationExponential Smoothing
Exponenial moohing Inroducion A simple mehod for forecasing. Does no require long series. Enables o decompose he series ino a rend and seasonal effecs. Paricularly useful mehod when here is a need o forecas
More informationGeneralized Least Squares
Generalized Leas Squares Augus 006 1 Modified Model Original assumpions: 1 Specificaion: y = Xβ + ε (1) Eε =0 3 EX 0 ε =0 4 Eεε 0 = σ I In his secion, we consider relaxing assumpion (4) Insead, assume
More informationSolutions to Odd Number Exercises in Chapter 6
1 Soluions o Odd Number Exercises in 6.1 R y eˆ 1.7151 y 6.3 From eˆ ( T K) ˆ R 1 1 SST SST SST (1 R ) 55.36(1.7911) we have, ˆ 6.414 T K ( ) 6.5 y ye ye y e 1 1 Consider he erms e and xe b b x e y e b
More informationBox-Jenkins Modelling of Nigerian Stock Prices Data
Greener Journal of Science Engineering and Technological Research ISSN: 76-7835 Vol. (), pp. 03-038, Sepember 0. Research Aricle Box-Jenkins Modelling of Nigerian Sock Prices Daa Ee Harrison Euk*, Barholomew
More informationSection 4 NABE ASTEF 232
Secion 4 NABE ASTEF 3 APPLIED ECONOMETRICS: TIME-SERIES ANALYSIS 33 Inroducion and Review The Naure of Economic Modeling Judgemen calls unavoidable Economerics an ar Componens of Applied Economerics Specificaion
More information5. NONLINEAR MODELS [1] Nonlinear (NL) Regression Models
5. NONLINEAR MODELS [1] Nonlinear (NL) Regression Models General form of nonlinear or linear regression models: y = h(x,β) + ε, ε iid N(0,σ ). Assume ha he x and ε sochasically independen. his assumpion
More informationKriging Models Predicting Atrazine Concentrations in Surface Water Draining Agricultural Watersheds
1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 Kriging Models Predicing Arazine Concenraions in Surface Waer Draining Agriculural Waersheds Paul L. Mosquin, Jeremy Aldworh, Wenlin Chen Supplemenal Maerial Number
More informationDEPARTMENT OF STATISTICS
A Tes for Mulivariae ARCH Effecs R. Sco Hacker and Abdulnasser Haemi-J 004: DEPARTMENT OF STATISTICS S-0 07 LUND SWEDEN A Tes for Mulivariae ARCH Effecs R. Sco Hacker Jönköping Inernaional Business School
More informationCHAPTER 17: DYNAMIC ECONOMETRIC MODELS: AUTOREGRESSIVE AND DISTRIBUTED-LAG MODELS
Basic Economerics, Gujarai and Porer CHAPTER 7: DYNAMIC ECONOMETRIC MODELS: AUTOREGRESSIVE AND DISTRIBUTED-LAG MODELS 7. (a) False. Economeric models are dynamic if hey porray he ime pah of he dependen
More informationDepartment of Economics East Carolina University Greenville, NC Phone: Fax:
March 3, 999 Time Series Evidence on Wheher Adjusmen o Long-Run Equilibrium is Asymmeric Philip Rohman Eas Carolina Universiy Absrac The Enders and Granger (998) uni-roo es agains saionary alernaives wih
More informationØkonomisk Kandidateksamen 2005(II) Econometrics 2. Solution
Økonomisk Kandidaeksamen 2005(II) Economerics 2 Soluion his is he proposed soluion for he exam in Economerics 2. For compleeness he soluion gives formal answers o mos of he quesions alhough his is no always
More informationTÁMOP /2/A/KMR
ECONOMIC STATISTICS ECONOMIC STATISTICS Sonsored by a Gran TÁMOP-4..2-08/2/A/KMR-2009-004 Course Maerial Develoed by Dearmen of Economics, Faculy of Social Sciences, Eövös Loránd Universiy Budaes (ELTE)
More informationEstimation Uncertainty
Esimaion Uncerainy The sample mean is an esimae of β = E(y +h ) The esimaion error is = + = T h y T b ( ) = = + = + = = = T T h T h e T y T y T b β β β Esimaion Variance Under classical condiions, where
More informationChapter 5. Heterocedastic Models. Introduction to time series (2008) 1
Chaper 5 Heerocedasic Models Inroducion o ime series (2008) 1 Chaper 5. Conens. 5.1. The ARCH model. 5.2. The GARCH model. 5.3. The exponenial GARCH model. 5.4. The CHARMA model. 5.5. Random coefficien
More informationSolutions: Wednesday, November 14
Amhers College Deparmen of Economics Economics 360 Fall 2012 Soluions: Wednesday, November 14 Judicial Daa: Cross secion daa of judicial and economic saisics for he fify saes in 2000. JudExp CrimesAll
More information14 Autoregressive Moving Average Models
14 Auoregressive Moving Average Models In his chaper an imporan parameric family of saionary ime series is inroduced, he family of he auoregressive moving average, or ARMA, processes. For a large class
More information(10) (a) Derive and plot the spectrum of y. Discuss how the seasonality in the process is evident in spectrum.
January 01 Final Exam Quesions: Mark W. Wason (Poins/Minues are given in Parenheses) (15) 1. Suppose ha y follows he saionary AR(1) process y = y 1 +, where = 0.5 and ~ iid(0,1). Le x = (y + y 1 )/. (11)
More informationLONG MEMORY AT THE LONG-RUN AND THE SEASONAL MONTHLY FREQUENCIES IN THE US MONEY STOCK. Guglielmo Maria Caporale. Brunel University, London
LONG MEMORY AT THE LONG-RUN AND THE SEASONAL MONTHLY FREQUENCIES IN THE US MONEY STOCK Guglielmo Maria Caporale Brunel Universiy, London Luis A. Gil-Alana Universiy of Navarra Absrac In his paper we show
More informationModeling Economic Time Series with Stochastic Linear Difference Equations
A. Thiemer, SLDG.mcd, 6..6 FH-Kiel Universiy of Applied Sciences Prof. Dr. Andreas Thiemer e-mail: andreas.hiemer@fh-kiel.de Modeling Economic Time Series wih Sochasic Linear Difference Equaions Summary:
More informationSolutions to Exercises in Chapter 12
Chaper in Chaper. (a) The leas-squares esimaed equaion is given by (b)!i = 6. + 0.770 Y 0.8 R R = 0.86 (.5) (0.07) (0.6) Boh b and b 3 have he expeced signs; income is expeced o have a posiive effec on
More informationHow to Deal with Structural Breaks in Practical Cointegration Analysis
How o Deal wih Srucural Breaks in Pracical Coinegraion Analysis Roselyne Joyeux * School of Economic and Financial Sudies Macquarie Universiy December 00 ABSTRACT In his noe we consider he reamen of srucural
More informationTypes of Exponential Smoothing Methods. Simple Exponential Smoothing. Simple Exponential Smoothing
M Business Forecasing Mehods Exponenial moohing Mehods ecurer : Dr Iris Yeung Room No : P79 Tel No : 788 8 Types of Exponenial moohing Mehods imple Exponenial moohing Double Exponenial moohing Brown s
More informationThe Effect of Nonzero Autocorrelation Coefficients on the Distributions of Durbin-Watson Test Estimator: Three Autoregressive Models
EJ Exper Journal of Economi c s ( 4 ), 85-9 9 4 Th e Au h or. Publi sh ed by Sp rin In v esify. ISS N 3 5 9-7 7 4 Econ omics.e xp erjou rn a ls.com The Effec of Nonzero Auocorrelaion Coefficiens on he
More informationGMM - Generalized Method of Moments
GMM - Generalized Mehod of Momens Conens GMM esimaion, shor inroducion 2 GMM inuiion: Maching momens 2 3 General overview of GMM esimaion. 3 3. Weighing marix...........................................
More informationAn Overview of Methods for Testing Short- and Long-Run Equilibrium with Time Series Data: Cointegration and Error Correction Mechanism
ISSN 2039-9340 (prin) Medierranean Journal of Social Sciences Published by MCSER-CEMAS-Sapienza Universiy of Rome An Overview of Mehods for Tesing Shor- and Long-Run Equilibrium wih Time Series Daa: Coinegraion
More informationDerived Short-Run and Long-Run Softwood Lumber Demand and Supply
Derived Shor-Run and Long-Run Sofwood Lumber Demand and Supply Nianfu Song and Sun Joseph Chang School of Renewable Naural Resources Louisiana Sae Universiy Ouline Shor-run run and long-run implied by
More informationRemittances and Economic Growth: Empirical Evidence from Bangladesh
Journal of Economics and Susainable Developmen ISSN 2222-700 (Paper) ISSN 2222-2855 (Online) Vol.7, No.2, 206 www.iise.org Remiances and Economic Growh: Empirical Evidence from Bangladesh Md. Nisar Ahmed
More informationY, where. 1 Estimate St.error
1 HG Feb 2014 ECON 5101 Exercises III - 24 Feb 2014 Exercise 1 In lecure noes 3 (LN3 page 11) we esimaed an ARMA(1,2) for daa) for he period, 1978q2-2013q2 Le Y ln BNP ln BNP (Norwegian Model: Y Y, where
More informationA Hybrid Model for Improving. Malaysian Gold Forecast Accuracy
In. Journal of Mah. Analysis, Vol. 8, 2014, no. 28, 1377-1387 HIKARI Ld, www.m-hikari.com hp://dx.doi.org/10.12988/ijma.2014.45139 A Hybrid Model for Improving Malaysian Gold Forecas Accuracy Maizah Hura
More informationBrief Sketch of Solutions: Tutorial 3. 3) unit root tests
Brief Sketch of Solutions: Tutorial 3 3) unit root tests.5.4.4.3.3.2.2.1.1.. -.1 -.1 -.2 -.2 -.3 -.3 -.4 -.4 21 22 23 24 25 26 -.5 21 22 23 24 25 26.8.2.4. -.4 - -.8 - - -.12 21 22 23 24 25 26 -.2 21 22
More informationESTIMATION OF DYNAMIC PANEL DATA MODELS WHEN REGRESSION COEFFICIENTS AND INDIVIDUAL EFFECTS ARE TIME-VARYING
Inernaional Journal of Social Science and Economic Research Volume:02 Issue:0 ESTIMATION OF DYNAMIC PANEL DATA MODELS WHEN REGRESSION COEFFICIENTS AND INDIVIDUAL EFFECTS ARE TIME-VARYING Chung-ki Min Professor
More informationWhy is Chinese Provincial Output Diverging? Joakim Westerlund, University of Gothenburg David Edgerton, Lund University Sonja Opper, Lund University
Why is Chinese Provincial Oupu Diverging? Joakim Weserlund, Universiy of Gohenburg David Edgeron, Lund Universiy Sonja Opper, Lund Universiy Purpose of his paper. We re-examine he resul of Pedroni and
More information3.1 More on model selection
3. More on Model selecion 3. Comparing models AIC, BIC, Adjused R squared. 3. Over Fiing problem. 3.3 Sample spliing. 3. More on model selecion crieria Ofen afer model fiing you are lef wih a handful of
More informationWednesday, December 5 Handout: Panel Data and Unobservable Variables
Amhers College Deparmen of Economics Economics 360 Fall 0 Wednesday, December 5 Handou: Panel Daa and Unobservable Variables Preview Taking Sock: Ordinary Leas Squares (OLS) Esimaion Procedure o Sandard
More informationNonstationary Time Series Data and Cointegration
ECON 4551 Economerics II Memorial Universiy of Newfoundland Nonsaionary Time Series Daa and Coinegraion Adaped from Vera Tabakova s noes 12.1 Saionary and Nonsaionary Variables 12.2 Spurious Regressions
More information12: AUTOREGRESSIVE AND MOVING AVERAGE PROCESSES IN DISCRETE TIME. Σ j =
1: AUTOREGRESSIVE AND MOVING AVERAGE PROCESSES IN DISCRETE TIME Moving Averages Recall ha a whie noise process is a series { } = having variance σ. The whie noise process has specral densiy f (λ) = of
More informationACE 562 Fall Lecture 4: Simple Linear Regression Model: Specification and Estimation. by Professor Scott H. Irwin
ACE 56 Fall 005 Lecure 4: Simple Linear Regression Model: Specificaion and Esimaion by Professor Sco H. Irwin Required Reading: Griffihs, Hill and Judge. "Simple Regression: Economic and Saisical Model
More information10. State Space Methods
. Sae Space Mehods. Inroducion Sae space modelling was briefly inroduced in chaper. Here more coverage is provided of sae space mehods before some of heir uses in conrol sysem design are covered in he
More informationACE 564 Spring Lecture 7. Extensions of The Multiple Regression Model: Dummy Independent Variables. by Professor Scott H.
ACE 564 Spring 2006 Lecure 7 Exensions of The Muliple Regression Model: Dumm Independen Variables b Professor Sco H. Irwin Readings: Griffihs, Hill and Judge. "Dumm Variables and Varing Coefficien Models
More informationEmpirical Process Theory
Empirical Process heory 4.384 ime Series Analysis, Fall 27 Reciaion by Paul Schrimpf Supplemenary o lecures given by Anna Mikusheva Ocober 7, 28 Reciaion 7 Empirical Process heory Le x be a real-valued
More informationt is a basis for the solution space to this system, then the matrix having these solutions as columns, t x 1 t, x 2 t,... x n t x 2 t...
Mah 228- Fri Mar 24 5.6 Marix exponenials and linear sysems: The analogy beween firs order sysems of linear differenial equaions (Chaper 5) and scalar linear differenial equaions (Chaper ) is much sronger
More informationMath 2142 Exam 1 Review Problems. x 2 + f (0) 3! for the 3rd Taylor polynomial at x = 0. To calculate the various quantities:
Mah 4 Eam Review Problems Problem. Calculae he 3rd Taylor polynomial for arcsin a =. Soluion. Le f() = arcsin. For his problem, we use he formula f() + f () + f ()! + f () 3! for he 3rd Taylor polynomial
More informationCointegration in Theory and Practice. A Tribute to Clive Granger. ASSA Meetings January 5, 2010
Coinegraion in heory and Pracice A ribue o Clive Granger ASSA Meeings January 5, 00 James H. Sock Deparmen of Economics, Harvard Universiy and he NBER /4/009 /4/009 Coinegraion: he Hisorical Seing Granger
More informationSome Basic Information about M-S-D Systems
Some Basic Informaion abou M-S-D Sysems 1 Inroducion We wan o give some summary of he facs concerning unforced (homogeneous) and forced (non-homogeneous) models for linear oscillaors governed by second-order,
More informationACE 562 Fall Lecture 5: The Simple Linear Regression Model: Sampling Properties of the Least Squares Estimators. by Professor Scott H.
ACE 56 Fall 005 Lecure 5: he Simple Linear Regression Model: Sampling Properies of he Leas Squares Esimaors by Professor Sco H. Irwin Required Reading: Griffihs, Hill and Judge. "Inference in he Simple
More informationTesting for Cointegration in Misspecified Systems A Monte Carlo Study of Size Distortions
Tesing for Coinegraion in Misspecified Sysems A Mone Carlo Sudy of Size Disorions Pär Öserholm * Augus 2003 Absrac When dealing wih ime series ha are inegraed of order one, he concep of coinegraion becomes
More informationState-Space Models. Initialization, Estimation and Smoothing of the Kalman Filter
Sae-Space Models Iniializaion, Esimaion and Smoohing of he Kalman Filer Iniializaion of he Kalman Filer The Kalman filer shows how o updae pas predicors and he corresponding predicion error variances when
More informationDynamic Models, Autocorrelation and Forecasting
ECON 4551 Economerics II Memorial Universiy of Newfoundland Dynamic Models, Auocorrelaion and Forecasing Adaped from Vera Tabakova s noes 9.1 Inroducion 9.2 Lags in he Error Term: Auocorrelaion 9.3 Esimaing
More informationForecasting optimally
I) ile: Forecas Evaluaion II) Conens: Evaluaing forecass, properies of opimal forecass, esing properies of opimal forecass, saisical comparison of forecas accuracy III) Documenaion: - Diebold, Francis
More informationECON 482 / WH Hong Time Series Data Analysis 1. The Nature of Time Series Data. Example of time series data (inflation and unemployment rates)
ECON 48 / WH Hong Time Series Daa Analysis. The Naure of Time Series Daa Example of ime series daa (inflaion and unemploymen raes) ECON 48 / WH Hong Time Series Daa Analysis The naure of ime series daa
More informationVolatility. Many economic series, and most financial series, display conditional volatility
Volailiy Many economic series, and mos financial series, display condiional volailiy The condiional variance changes over ime There are periods of high volailiy When large changes frequenly occur And periods
More informationThe Simple Linear Regression Model: Reporting the Results and Choosing the Functional Form
Chaper 6 The Simple Linear Regression Model: Reporing he Resuls and Choosing he Funcional Form To complee he analysis of he simple linear regression model, in his chaper we will consider how o measure
More informationMeasurement Error 1: Consequences Page 1. Definitions. For two variables, X and Y, the following hold: Expectation, or Mean, of X.
Measuremen Error 1: Consequences of Measuremen Error Richard Williams, Universiy of Nore Dame, hps://www3.nd.edu/~rwilliam/ Las revised January 1, 015 Definiions. For wo variables, X and Y, he following
More informationThe Validity of the Tourism-Led Growth Hypothesis for Thailand
MPRA Munich Personal RePEc Archive The Validiy of he Tourism-Led Growh Hypohesis for Thailand Komain Jiranyakul Naional Insiue of Developmen Adminisraion Augus 206 Online a hps://mpra.ub.uni-muenchen.de/72806/
More informationStability. Coefficients may change over time. Evolution of the economy Policy changes
Sabiliy Coefficiens may change over ime Evoluion of he economy Policy changes Time Varying Parameers y = α + x β + Coefficiens depend on he ime period If he coefficiens vary randomly and are unpredicable,
More informationDo Steel Consumption and Production Cause Economic Growth?: A Case Study of Six Southeast Asian Countries
JOURNAL OF INTERNATIONAL AND AREA STUDIES Volume 5, Number, 008, pp.-5 Do Seel Consumpion and Producion Cause Economic Growh?: A Case Sudy of Six Souheas Asian Counries Hee-Ryang Ra This sudy aims o deermine
More informationForecast of Adult Literacy in Sudan
Journal for Sudies in Managemen and Planning Available a hp://inernaionaljournalofresearch.org/index.php/jsmap e-issn: 2395-463 Volume 1 Issue 2 March 215 Forecas of Adul Lieracy in Sudan Dr. Elfarazdag
More information3.1.3 INTRODUCTION TO DYNAMIC OPTIMIZATION: DISCRETE TIME PROBLEMS. A. The Hamiltonian and First-Order Conditions in a Finite Time Horizon
3..3 INRODUCION O DYNAMIC OPIMIZAION: DISCREE IME PROBLEMS A. he Hamilonian and Firs-Order Condiions in a Finie ime Horizon Define a new funcion, he Hamilonian funcion, H. H he change in he oal value of
More informationSmoothing. Backward smoother: At any give T, replace the observation yt by a combination of observations at & before T
Smoohing Consan process Separae signal & noise Smooh he daa: Backward smooher: A an give, replace he observaion b a combinaion of observaions a & before Simple smooher : replace he curren observaion wih
More informationNotes on Kalman Filtering
Noes on Kalman Filering Brian Borchers and Rick Aser November 7, Inroducion Daa Assimilaion is he problem of merging model predicions wih acual measuremens of a sysem o produce an opimal esimae of he curren
More informationComparing Means: t-tests for One Sample & Two Related Samples
Comparing Means: -Tess for One Sample & Two Relaed Samples Using he z-tes: Assumpions -Tess for One Sample & Two Relaed Samples The z-es (of a sample mean agains a populaion mean) is based on he assumpion
More information1. Diagnostic (Misspeci cation) Tests: Testing the Assumptions
Business School, Brunel Universiy MSc. EC5501/5509 Modelling Financial Decisions and Markes/Inroducion o Quaniaive Mehods Prof. Menelaos Karanasos (Room SS269, el. 01895265284) Lecure Noes 6 1. Diagnosic
More informationCOINTEGRATION: A REVIEW JIE ZHANG. B.A., Peking University, 2006 A REPORT. submitted in partial fulfillment of the requirements for the degree
COINTEGRATION: A REVIEW by JIE ZHANG B.A., Peking Universiy, A REPORT submied in parial fulfillmen of he requiremens for he degree MASTER OF SCIENCE Deparmen of Saisics College of Ars And Sciences KANSAS
More informationRobust critical values for unit root tests for series with conditional heteroscedasticity errors: An application of the simple NoVaS transformation
WORKING PAPER 01: Robus criical values for uni roo ess for series wih condiional heeroscedasiciy errors: An applicaion of he simple NoVaS ransformaion Panagiois Manalos ECONOMETRICS AND STATISTICS ISSN
More informationLecture 3: Exponential Smoothing
NATCOR: Forecasing & Predicive Analyics Lecure 3: Exponenial Smoohing John Boylan Lancaser Cenre for Forecasing Deparmen of Managemen Science Mehods and Models Forecasing Mehod A (numerical) procedure
More information