LONG MEMORY AT THE LONG-RUN AND THE SEASONAL MONTHLY FREQUENCIES IN THE US MONEY STOCK. Guglielmo Maria Caporale. Brunel University, London
|
|
- Rafe Bennett
- 6 years ago
- Views:
Transcription
1 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 ha he monhly srucure of he US money sock can be specified in erms of a long-memory process, wih roos a boh he zero and he seasonal monhly frequencies. We use a procedure ha enables us o es simulaneously for he roos a all hese frequencies. The resuls show ha he roo a he long-run or zero frequency plays a much more imporan role han he seasonal one, hough he laer should also be aken ino accoun. Keywords: Seasonaliy, Long Memory, Fracional Inegraion JEL Classificaion: C5; C Corresponding auhor: Professor Guglielmo Maria Caporale, Brunel Business School, Brunel Universiy, Uxbridge, Middlesex UB8 3PH, UK. Tel.: +44 (0) Fax: +44 (0) Guglielmo-Maria.Caporale@brunel.ac.uk The second named auhor graefully acknowledges financial suppor from he PIUNA Proec a he Universiy of Navarra, Pamplona, Spain.
2 . Inroducion Dickey, Hasza and Fuller (DHF, 984), Hylleberg, Engle, Granger and Yoo (HEGY, 990), Beaulieu and Miron (993), and Tam and Reinsel (998), amongs ohers, have proposed es saisics for seasonal uni roos in raw ime series. More precisely, if x is he ime series we observe, wih a changing seasonal paern, we can consider he model s ( L ) x u,,,..., () where s is he number of ime periods in a year, and u is an I(0) process, defined for he purposes of he presen paper as a covariance-saionary process wih specral densiy ha is posiive and finie a any frequency. Noe ha he polynomial in () can be decomposed ino ( L)( + L + L L s ) ( L) S( L). Tha is, he seasonal difference operaor can be wrien as he produc of he firs difference operaor and he moving-average filer S(L), conaining furher roos of modulus uniy. The roo a he long-run or zero frequency hen appears as a componen of he seasonal polynomial in (). However, here are many cases when his frequency plays a maor role, accouning no only for some of he seasonal behaviour bu also for he rending sochasic behaviour of he series. In his paper, we focus on monhly daa, (i.e. s ), and presen a version of he esing procedure of Robinson (994) ha enables us o consider simulaneously uni roos wih possibly fracional orders of inegraion a boh he zero and he seasonal frequencies. In paricular, we examine models such as: d ( L) ( L d ) x u,,,..., () for given real values d and d. Here, he firs fracional polynomial can be expressed in erms of is binomial expansion such ha, for all real values d, d ( ) d L ( ) d ( d ) L L d L , and similarly, for he seasonal componen,
3 d ( ) d L ( ) ( d ) L 4 L d L + 0 d.... Clearly, seing d and d 0 in () amouns o esing he classical uni roo model (Dickey and Fuller, 979; Phillips, 987; ec); if d 0 and d, we have seasonal uni roos (e.g., HEGY, 990), and if d d, we obain he airline model inroduced by Box and Jenkins (976).. The esing procedure We use a simple version of he ess of Robinson (994), specifically a Lagrange Muliplier (LM) es of he null hypohesis: H o : d o o o ( d, d )' ( d, d )' d, (3) in () for given real numbers d o and d o. The es saisic is given by: ˆ T ˆ' ˆ R a A aˆ, (4) 4 ˆ σ where T is he sample size, and aˆ π T * ψ ( ) g( ; ˆ) τ I( ) ; π ˆ σ σ ( ˆ) τ g( ; ˆ) τ I( ), T T Aˆ * * * * ψ ( ) ψ ( )' ψ ( ) ˆ( ε )' ˆ( ε ) ˆ( ε )' ˆ( ε ) ψ ( )' T ψ ( )' [ ψ ( ), ψ ( )]; ˆ ε( ) log ( ; ˆ g τ ) ; ψ ( ) log sin ; τ ψ ( ) log sin + log cos + log cos + π log cos cos 3 + π + log cos cos 3 + π log cos cos 6 + 5π log cos cos, 6
4 wih π/t. I( ) is he periodogram of ˆ u d0 d o ( L) ( L ) x, and τˆ arg min τ T σ ( ), wih T * as a suiable subse of he R q Euclidean space. Finally, he funcion * τ g above is a known funcion coming from he specral densiy of u : f ( ; τ ) σ g( ; τ ), π π < π. Noe ha hese ess are purely parameric, and herefore require specific modelling assumpions abou he shor-memory specificaion of u. For insance, if u is a whie noise process, g, whils if u is an AR process of he form φ(l)u ε, hen g φ(e i ) -, wih σ V(ε ), he AR coefficiens being a funcion of τ. Based on H o (3), Robinson (994) esablished ha, under cerain regulariy condiions: Rˆ d χ, as T. (5) Thus, unlike oher procedures, we are in a classical large-sample esing siuaion for he reasons oulined by Robinson (994), who also showed ha he ess are efficien in he Piman sense agains local deparures from he null. A es of (3) will reec H o agains he alernaive χ, α χ, α χ H a : d d o if Rˆ >, where Prob ( > ) α. There exis oher versions of he ess of Robinson (994), esing, for example, only he roo a he long-run or zero frequency (e.g., Gil-Alana and Robinson, 997; Gil-Alana, 000), purely seasonal fracional models (Gil- Alana, 999, 00; Gil-Alana and Robinson, 00), or cyclical srucures (Gil-Alana, 00). However, a simulaneous es for he roos a boh he zero and he seasonal monhly componens has no been implemened ye. We carry ou such a es in he following secion. 3. Tesing for he orders of inegraion of he US monhly money sock The ime series analysed in his secion is he (seasonally unadused) US monhly money sock (billions of dollars), for he ime period 947m o 00m8, obained from he Federal Reserve Bank of S. Louis daabase. 3
5 Denoing he ime series x, we employ hroughou model (), esing H o (3) for values d o, d o 0, (0.5),, hereby including ess for a uni roo exclusively a he long-run or zero frequency (d o, d o 0), as well as ess for seasonal uni roos (d o 0, d o ), and uni and seasonal uni roos (d o d o ), in addiion o oher fracionally inegraed possibiliies. Iniially, we assume ha u is whie noise, bu hen we also allow for weakly paramerically auocorrelaed disurbances. In paricular, we consider AR() and seasonally monhly AR() processes for u. Only one non-reecion occurs for he hree ypes of disurbances, corresponding o (d o, d o ) (.5, 0.5). This suggess ha he order of inegraion a he longrun frequency has a much more imporan role han he one corresponding o he seasonal frequency. (Inser Figure abou here) In order o have a more precise view abou he non-reecion values, we performed again he ess of Robinson (994), bu his ime using incremens of 0.0 for d o and d o. Figure displays he non-reecion regions of (d o, d o ) for each ype of disurbances. I can be seen ha in all cases d o is higher han d o, highlighing once more he imporance of he roo a he zero frequency. In paricular, d o appears o be consrained beween. and.5, whils d o oscillaes around 0.5. Consequenly, shocks o he long-run componen will have permanen effecs, policy acions being required o bring he series back o is original rend. On he oher hand, seasonal shocks will be ransiory, mean reversion occurring a some poin in he fuure. Nex, we ry o esablish wha migh be he bes model specificaion for his series. For his purpose, we compue, for each model, he values of d o and d o producing he lowes saisics, which should be an approximaion of he maximum likelihood esimaes; his is because he procedure employed here is a Lagrange Muliplier es and is based on he While funcion, which is an approximaion o he likelihood funcion. The parameer values are displayed in Table. (Inser Table abou here) 4
6 I can be seen ha, if u is whie noise, d.7 and d 0.4; he corresponding values if u is AR() are d.0 and d 0.09; finally, if u is modelled as a seasonal AR() process, d. and d 0.9. Thus, in all hree cases he order of inegraion a he zero frequency is higher han, whils he seasonal one is slighly above 0. Several diagnosic ess were hen carried ou on he residuals of he esimaed models, indicaing ha he bes model is he one wih seasonal AR disurbances. Our preferred specificaion is herefore he following: (. L) 0.9 ( L ) x u,,,... u 0.43u + ε,,,... wih whie noise ε. Clearly, he sandard approach of aking firs differences or firs seasonal differences would no appropriae here, since he former would resul in a series sill exhibiing a long-memory componen, whils he laer would enail overdifferencing. 4. Conclusions The sochasic behaviour of he US money sock has been examined in his paper using a procedure ha enables us o consider simulaneously roos wih fracional orders of inegraion boh a he zero and he seasonal frequencies. The resuls sugges ha he roo a he zero frequency should be considered independenly of he seasonal frequency, hough he laer should also be aken ino accoun, exhibiing an order of inegraion of abou 0.5. Finally, he fac ha he roo a he long-run frequency is higher han, while he one affecing he seasonal srucure is smaller han, has some implicaions in erms of policy acion and forecasing. In paricular, whils shocks affecing he seasonal srucure appear o be mean revering, hose affecing he long run end o persis forever, requiring policy-makers o ake appropriae acions o resore equilibrium. 5
7 References Beaulieu, J.J. and J.A. Miron, 993, Seasonal uni roos in aggregae U.S. daa, Journal of Economerics 55, Box, G.E.P. and G.M. Jenkins, 976, Time Series Analysis: Forecasing and Conrol, ( nd eds.) San Francisco, C.A.: Holden-Day. Dickey, D. A., D. P. Hasza and W. A. Fuller, 984, Tesing for uni roos in seasonal ime series, Journal of he American Saisical Associaion 79, Gil-Alana, L.A., 999, Tesing fracional inegraion wih monhly daa, Economic Modelling 6, Gil-Alana, L.A., 000, Mean reversion in he real exchange raes, Economics Leers 69, Gil-Alana, L.A., 00, Tesing sochasic cycles in macroeconomic ime series, Journal of Time Series Analysis, Gil-Alana, L.A., 00, Seasonal long memory in he aggregae oupu, Economics Leers 74, Gil-Alana, L.A. and P.M. Robinson, 997, Tesing of uni roos and oher nonsaionary hypoheses in macroeconomic ime series, Journal of Economerics 80, Gil-Alana, L.A. and P.M. Robinson, 00, Tesing seasonal fracional inegraion in he UK and Japanese consumpion and income, Journal of Applied Economerics 6, Hylleberg, S., R.F. Engle, C.W.J. Granger and B.S. Yoo, 990, Seasonal inegraion and coinegraion, Journal of Economerics 44, Porer-Hudak, S., 990, An applicaion of he seasonal fracionally differenced model o he moneary aggregaes, Journal of he American Saisical Associaion 85, Robinson, P.M., 994, Efficien ess of nonsaionary hypoheses, Journal of he American Saisical Associaion 89, Tam, W. and G. C. Reimsel, 997, Tess for seasonal moving average uni roo in ARIMA models, Journal of he American Saisical Associaion 9,
8 FIGURE Region of values of d o and d o where H o (3) canno be reeced a he 95% significance level i) wih whie noise disurbances: 0,75 d 0,5 0,5 0,,,3,4,5 d ii) wih AR() disurbances: 0,75 d 0,5 0,5 0,,,3,4,5 d iii) wih seasonal AR() disurbances: 0,75 d 0,5 0,5 0,,,3,4,5 d 7
9 TABLE Model specificaions according o he lowes saisics in Figure u d d AR coeff. Seasonal AR coeff. Whie noise AR () Seasonal AR()
GDP PER CAPITA IN EUROPE: TIME TRENDS AND PERSISTENCE
Economics and Finance Working Paper Series Deparmen of Economics and Finance Working Paper No. 17-18 Guglielmo Maria Caporale and Luis A. Gil-Alana GDP PER CAPITA IN EUROPE: TIME TRENDS AND PERSISTENCE
More informationSTRUCTURAL CHANGE IN TIME SERIES OF THE EXCHANGE RATES BETWEEN YEN-DOLLAR AND YEN-EURO IN
Inernaional Journal of Applied Economerics and Quaniaive Sudies. Vol.1-3(004) STRUCTURAL CHANGE IN TIME SERIES OF THE EXCHANGE RATES BETWEEN YEN-DOLLAR AND YEN-EURO IN 001-004 OBARA, Takashi * Absrac The
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 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 informationProblem Set 5. Graduate Macro II, Spring 2017 The University of Notre Dame Professor Sims
Problem Se 5 Graduae Macro II, Spring 2017 The Universiy of Nore Dame Professor Sims Insrucions: You may consul wih oher members of he class, bu please make sure o urn in your own work. Where applicable,
More informationCointegration and Implications for Forecasting
Coinegraion and Implicaions for Forecasing Two examples (A) Y Y 1 1 1 2 (B) Y 0.3 0.9 1 1 2 Example B: Coinegraion Y and coinegraed wih coinegraing vecor [1, 0.9] because Y 0.9 0.3 is a saionary process
More informationA unit root test based on smooth transitions and nonlinear adjustment
MPRA Munich Personal RePEc Archive A uni roo es based on smooh ransiions and nonlinear adjusmen Aycan Hepsag Isanbul Universiy 5 Ocober 2017 Online a hps://mpra.ub.uni-muenchen.de/81788/ MPRA Paper No.
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 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 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 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 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 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 informationDYNAMIC ECONOMETRIC MODELS Vol. 4 Nicholas Copernicus University Toruń Jacek Kwiatkowski Nicholas Copernicus University in Toruń
DYNAMIC ECONOMETRIC MODELS Vol. 4 Nicholas Copernicus Universiy Toruń 000 Jacek Kwiakowski Nicholas Copernicus Universiy in Toruń Bayesian analysis of long memory and persisence using ARFIMA models wih
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 informationTesting for a Single Factor Model in the Multivariate State Space Framework
esing for a Single Facor Model in he Mulivariae Sae Space Framework Chen C.-Y. M. Chiba and M. Kobayashi Inernaional Graduae School of Social Sciences Yokohama Naional Universiy Japan Faculy of Economics
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 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 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 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 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 informationVehicle Arrival Models : Headway
Chaper 12 Vehicle Arrival Models : Headway 12.1 Inroducion Modelling arrival of vehicle a secion of road is an imporan sep in raffic flow modelling. I has imporan applicaion in raffic flow simulaion where
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 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 informationGranger Causality Among Pre-Crisis East Asian Exchange Rates. (Running Title: Granger Causality Among Pre-Crisis East Asian Exchange Rates)
Granger Causaliy Among PreCrisis Eas Asian Exchange Raes (Running Tile: Granger Causaliy Among PreCrisis Eas Asian Exchange Raes) Joseph D. ALBA and Donghyun PARK *, School of Humaniies and Social Sciences
More informationHas the Business Cycle Changed? Evidence and Explanations. Appendix
Has he Business Ccle Changed? Evidence and Explanaions Appendix Augus 2003 James H. Sock Deparmen of Economics, Harvard Universi and he Naional Bureau of Economic Research and Mark W. Wason* Woodrow Wilson
More informationMacroeconomic Theory Ph.D. Qualifying Examination Fall 2005 ANSWER EACH PART IN A SEPARATE BLUE BOOK. PART ONE: ANSWER IN BOOK 1 WEIGHT 1/3
Macroeconomic Theory Ph.D. Qualifying Examinaion Fall 2005 Comprehensive Examinaion UCLA Dep. of Economics You have 4 hours o complee he exam. There are hree pars o he exam. Answer all pars. Each par has
More informationDYNAMIC ECONOMETRIC MODELS vol NICHOLAS COPERNICUS UNIVERSITY - TORUŃ Józef Stawicki and Joanna Górka Nicholas Copernicus University
DYNAMIC ECONOMETRIC MODELS vol.. - NICHOLAS COPERNICUS UNIVERSITY - TORUŃ 996 Józef Sawicki and Joanna Górka Nicholas Copernicus Universiy ARMA represenaion for a sum of auoregressive processes In he ime
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 informationLONG RUN AND CYCLICAL DYNAMICS
LONG RUN AND CYCLICAL DYNAMICS IN THE US STOCK MARKET GUGLIELMO MARIA CAPORALE LUIS A. GIL-ALANA CESIFO WORKING PAPER NO. 46 CATEGORY 1: EMPIRICAL AND THEORETICAL METHODS JULY 7 An elecronic version of
More informationLong memory in US real output per capita. Guglielmo Maria Caporale and Luis A. Gil-Alana. January Department of Economics and Finance
Deparmen of Economics and Finance Working Paper No. 09-06 Economics and Finance Working Paper Series Guglielmo Maria Caporale and Luis A. Gil-Alana Long memory in US real oupu per capia January 009 hp://www.brunel.ac.uk/abou/acad/sss/deps/economics
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 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 information23.2. Representing Periodic Functions by Fourier Series. Introduction. Prerequisites. Learning Outcomes
Represening Periodic Funcions by Fourier Series 3. Inroducion In his Secion we show how a periodic funcion can be expressed as a series of sines and cosines. We begin by obaining some sandard inegrals
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 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 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 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 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 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 informationLong-run and Cyclical Dynamics in the US Stock Market
155 Reihe Ökonomie Economics Series Long-run and Cyclical Dynamics in he US Sock Marke Guglielmo Maria Caporale, Luis A. Gil-Alana 155 Reihe Ökonomie Economics Series Long-run and Cyclical Dynamics in
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 informationLecture Notes 2. The Hilbert Space Approach to Time Series
Time Series Seven N. Durlauf Universiy of Wisconsin. Basic ideas Lecure Noes. The Hilber Space Approach o Time Series The Hilber space framework provides a very powerful language for discussing he relaionship
More informationDEPARTMENT OF ECONOMICS AND FINANCE COLLEGE OF BUSINESS AND ECONOMICS UNIVERSITY OF CANTERBURY CHRISTCHURCH, NEW ZEALAND
DEPARTMENT OF ECONOMICS AND FINANCE COLLEGE OF BUSINESS AND ECONOMICS UNIVERSITY OF CANTERBURY CHRISTCHURCH, NEW ZEALAND Asymmery and Leverage in Condiional Volailiy Models Michael McAleer WORKING PAPER
More informationMath 333 Problem Set #2 Solution 14 February 2003
Mah 333 Problem Se #2 Soluion 14 February 2003 A1. Solve he iniial value problem dy dx = x2 + e 3x ; 2y 4 y(0) = 1. Soluion: This is separable; we wrie 2y 4 dy = x 2 + e x dx and inegrae o ge The iniial
More informationQuarterly ice cream sales are high each summer, and the series tends to repeat itself each year, so that the seasonal period is 4.
Seasonal models Many business and economic ime series conain a seasonal componen ha repeas iself afer a regular period of ime. The smalles ime period for his repeiion is called he seasonal period, and
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 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 Dynamic Model of Economic Fluctuations
CHAPTER 15 A Dynamic Model of Economic Flucuaions Modified for ECON 2204 by Bob Murphy 2016 Worh Publishers, all righs reserved IN THIS CHAPTER, OU WILL LEARN: how o incorporae dynamics ino he AD-AS model
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 informationSTAD57 Time Series Analysis. Lecture 17
STAD57 Time Series Analysis Lecure 17 1 Exponenially Weighed Moving Average Model Consider ARIMA(0,1,1), or IMA(1,1), model 1 s order differences follow MA(1) X X W W Y X X W W 1 1 1 1 Very common model
More informationSTAD57 Time Series Analysis. Lecture 17
STAD57 Time Series Analysis Lecure 17 1 Exponenially Weighed Moving Average Model Consider ARIMA(0,1,1), or IMA(1,1), model 1 s order differences follow MA(1) X X W W Y X X W W 1 1 1 1 Very common model
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 informationFinal Exam Advanced Macroeconomics I
Advanced Macroeconomics I WS 00/ Final Exam Advanced Macroeconomics I February 8, 0 Quesion (5%) An economy produces oupu according o α α Y = K (AL) of which a fracion s is invesed. echnology A is exogenous
More informationT L. t=1. Proof of Lemma 1. Using the marginal cost accounting in Equation(4) and standard arguments. t )+Π RB. t )+K 1(Q RB
Elecronic Companion EC.1. Proofs of Technical Lemmas and Theorems LEMMA 1. Le C(RB) be he oal cos incurred by he RB policy. Then we have, T L E[C(RB)] 3 E[Z RB ]. (EC.1) Proof of Lemma 1. Using he marginal
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 informationExcel-Based Solution Method For The Optimal Policy Of The Hadley And Whittin s Exact Model With Arma Demand
Excel-Based Soluion Mehod For The Opimal Policy Of The Hadley And Whiin s Exac Model Wih Arma Demand Kal Nami School of Business and Economics Winson Salem Sae Universiy Winson Salem, NC 27110 Phone: (336)750-2338
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 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 informationNonlinearity Test on Time Series Data
PROCEEDING OF 3 RD INTERNATIONAL CONFERENCE ON RESEARCH, IMPLEMENTATION AND EDUCATION OF MATHEMATICS AND SCIENCE YOGYAKARTA, 16 17 MAY 016 Nonlineariy Tes on Time Series Daa Case Sudy: The Number of Foreign
More informationLecture Notes 3: Quantitative Analysis in DSGE Models: New Keynesian Model
Lecure Noes 3: Quaniaive Analysis in DSGE Models: New Keynesian Model Zhiwei Xu, Email: xuzhiwei@sju.edu.cn The moneary policy plays lile role in he basic moneary model wihou price sickiness. We now urn
More informationTime Series Test of Nonlinear Convergence and Transitional Dynamics. Terence Tai-Leung Chong
Time Series Tes of Nonlinear Convergence and Transiional Dynamics Terence Tai-Leung Chong Deparmen of Economics, The Chinese Universiy of Hong Kong Melvin J. Hinich Signal and Informaion Sciences Laboraory
More informationA note on spurious regressions between stationary series
A noe on spurious regressions beween saionary series Auhor Su, Jen-Je Published 008 Journal Tile Applied Economics Leers DOI hps://doi.org/10.1080/13504850601018106 Copyrigh Saemen 008 Rouledge. This is
More informationPhysics 127b: Statistical Mechanics. Fokker-Planck Equation. Time Evolution
Physics 7b: Saisical Mechanics Fokker-Planck Equaion The Langevin equaion approach o he evoluion of he velociy disribuion for he Brownian paricle migh leave you uncomforable. A more formal reamen of his
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 informationExplaining Total Factor Productivity. Ulrich Kohli University of Geneva December 2015
Explaining Toal Facor Produciviy Ulrich Kohli Universiy of Geneva December 2015 Needed: A Theory of Toal Facor Produciviy Edward C. Presco (1998) 2 1. Inroducion Toal Facor Produciviy (TFP) has become
More informationHypothesis Testing in the Classical Normal Linear Regression Model. 1. Components of Hypothesis Tests
ECONOMICS 35* -- NOTE 8 M.G. Abbo ECON 35* -- NOTE 8 Hypohesis Tesing in he Classical Normal Linear Regression Model. Componens of Hypohesis Tess. A esable hypohesis, which consiss of wo pars: Par : a
More informationOnline Appendix to Solution Methods for Models with Rare Disasters
Online Appendix o Soluion Mehods for Models wih Rare Disasers Jesús Fernández-Villaverde and Oren Levinal In his Online Appendix, we presen he Euler condiions of he model, we develop he pricing Calvo block,
More informationWavelet Variance, Covariance and Correlation Analysis of BSE and NSE Indexes Financial Time Series
Wavele Variance, Covariance and Correlaion Analysis of BSE and NSE Indexes Financial Time Series Anu Kumar 1*, Sangeea Pan 1, Lokesh Kumar Joshi 1 Deparmen of Mahemaics, Universiy of Peroleum & Energy
More informationSHIFTS IN PERSISTENCE IN TURKISH REAL EXCHANGE RATES HALUK ERLAT
Vol., Sepember 2009 SHIFTS IN PERSISTENCE IN TURKISH REAL EXCHANGE RATES HALUK ERLAT Deparmen of Economics Middle Eas Technical Universiy 0653 Ankara, Turkey Fax: 90-32-207964 Email: herla@meu.edu.r Prepared
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 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 informationRobust estimation based on the first- and third-moment restrictions of the power transformation model
h Inernaional Congress on Modelling and Simulaion, Adelaide, Ausralia, 6 December 3 www.mssanz.org.au/modsim3 Robus esimaion based on he firs- and hird-momen resricions of he power ransformaion Nawaa,
More informationThe Brock-Mirman Stochastic Growth Model
c December 3, 208, Chrisopher D. Carroll BrockMirman The Brock-Mirman Sochasic Growh Model Brock and Mirman (972) provided he firs opimizing growh model wih unpredicable (sochasic) shocks. The social planner
More informationA STRUCTURAL VECTOR ERROR CORRECTION MODEL WITH SHORT-RUN AND LONG-RUN RESTRICTIONS
199 THE KOREAN ECONOMIC REVIEW Volume 4, Number 1, Summer 008 A STRUCTURAL VECTOR ERROR CORRECTION MODEL WITH SHORT-RUN AND LONG-RUN RESTRICTIONS KYUNGHO JANG* We consider srucural vecor error correcion
More informationE β t log (C t ) + M t M t 1. = Y t + B t 1 P t. B t 0 (3) v t = P tc t M t Question 1. Find the FOC s for an optimum in the agent s problem.
Noes, M. Krause.. Problem Se 9: Exercise on FTPL Same model as in paper and lecure, only ha one-period govenmen bonds are replaced by consols, which are bonds ha pay one dollar forever. I has curren marke
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 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 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 informationSection 7.4 Modeling Changing Amplitude and Midline
488 Chaper 7 Secion 7.4 Modeling Changing Ampliude and Midline While sinusoidal funcions can model a variey of behaviors, i is ofen necessary o combine sinusoidal funcions wih linear and exponenial curves
More information- The whole joint distribution is independent of the date at which it is measured and depends only on the lag.
Saionary Processes Sricly saionary - The whole join disribuion is indeenden of he dae a which i is measured and deends only on he lag. - E y ) is a finie consan. ( - V y ) is a finie consan. ( ( y, y s
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 informationLAPLACE TRANSFORM AND TRANSFER FUNCTION
CHBE320 LECTURE V LAPLACE TRANSFORM AND TRANSFER FUNCTION Professor Dae Ryook Yang Spring 2018 Dep. of Chemical and Biological Engineering 5-1 Road Map of he Lecure V Laplace Transform and Transfer funcions
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 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 informationChoice of Spectral Density Estimator in Ng-Perron Test: A Comparative Analysis
Inernaional Economeric Review (IER) Choice of Specral Densiy Esimaor in Ng-Perron Tes: A Comparaive Analysis Muhammad Irfan Malik and Aiq-ur-Rehman Inernaional Islamic Universiy Islamabad and Inernaional
More informationThe electromagnetic interference in case of onboard navy ships computers - a new approach
The elecromagneic inerference in case of onboard navy ships compuers - a new approach Prof. dr. ing. Alexandru SOTIR Naval Academy Mircea cel Bărân, Fulgerului Sree, Consanţa, soiralexandru@yahoo.com Absrac.
More informationOn Measuring Pro-Poor Growth. 1. On Various Ways of Measuring Pro-Poor Growth: A Short Review of the Literature
On Measuring Pro-Poor Growh 1. On Various Ways of Measuring Pro-Poor Growh: A Shor eview of he Lieraure During he pas en years or so here have been various suggesions concerning he way one should check
More informationA Point Optimal Test for the Null of Near Integration. A. Aznar and M. I. Ayuda 1. University of Zaragoza
A Poin Opimal es for he Null of Near Inegraion A. Aznar and M. I. Ayuda Universiy of Zaragoza he objecive of his paper is o derive a poin opimal es for he null hypohesis of near inegraion (PONI-es). We
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 informationNCSS Statistical Software. , contains a periodic (cyclic) component. A natural model of the periodic component would be
NCSS Saisical Sofware Chaper 468 Specral Analysis Inroducion This program calculaes and displays he periodogram and specrum of a ime series. This is someimes nown as harmonic analysis or he frequency approach
More informationTesting for a unit root in a process exhibiting a structural break in the presence of GARCH errors
Tesing for a uni roo in a process exhibiing a srucural break in he presence of GARCH errors Aricle Acceped Version Brooks, C. and Rew, A. (00) Tesing for a uni roo in a process exhibiing a srucural break
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 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 information23.5. Half-Range Series. Introduction. Prerequisites. Learning Outcomes
Half-Range Series 2.5 Inroducion In his Secion we address he following problem: Can we find a Fourier series expansion of a funcion defined over a finie inerval? Of course we recognise ha such a funcion
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 informationMODELLING STRUCTURAL BREAKS IN THE US, UK AND JAPANESE UNEMPLOYMENT RATES. Guglielmo Maria Caporale Brunel University, London
MODELLING STRUCTURAL BREAKS IN THE US, UK AND JAPANESE UNEMPLOYMENT RATES Guglielmo Maria Caporale Brunel Universiy, London Luis A. Gil-Alana * Universiy of Navarra April 006 Absrac In his paper we use
More informationFinancial Crisis, Taylor Rule and the Fed
Deparmen of Economics Working Paper Series Financial Crisis, Taylor Rule and he Fed Saen Kumar 2014/02 1 Financial Crisis, Taylor Rule and he Fed Saen Kumar * Deparmen of Economics, Auckland Universiy
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 informationLecture 2 April 04, 2018
Sas 300C: Theory of Saisics Spring 208 Lecure 2 April 04, 208 Prof. Emmanuel Candes Scribe: Paulo Orensein; edied by Sephen Baes, XY Han Ouline Agenda: Global esing. Needle in a Haysack Problem 2. Threshold
More information