Modelling Seasonal Behaviour of Rainfall in Northeast Nigeria. A State Space Approach
|
|
- Erin Gallagher
- 5 years ago
- Views:
Transcription
1 Inernaional Journal of Saisics and Applicaions 216, 6(4): DOI: /j.saisics Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach O. J. Asemoa 1,*, M. A. Bamanga 2, O. J. Alaribe 1 1 Deparmen of Saisics, Universiy of Abuja, Abuja 2 Saisics Deparmen, Cenral Bank of Nigeria, Nigeria Absrac The modelling of seasonal behaviour of rainfall has become very imporan in he wake of he climaic change. Due o he agriculure base of he Norheas Nigeria, i is imperaive o explicily model seasonal behaviour of rainfall in he region for agriculural planning. Hence, his sudy examines he seasonal behaviour of monhly rainfall daa from 1981 o 213 in Maiduguri and Damauru areas of Borno and Yobe Saes respecively, using he sae space approach. We employed he local level model wih sochasic seasonal and he local level model wih deerminisic seasonal o modelling of he dynamic feaures in he daa. Our resuls clearly indicae ha he local level model wih deerminisic seasonal is he parsimonious model beween he wo sae space models considered in his sudy. This implies ha he seasonal paerns of rainfall in he wo areas have no significanly changed despie he challenges of global warming and climae change. In addiion, he CUSUM es indicaes he presence of srucural breaks in 1998 and 199 for Maiduguri and Damauru respecively. This implies ha here was an abrup change in he rainfall level in 1998 for Maiduguri and in 199 for Damauru. We, herefore, recommend ha seasonaliy should be explicily included in he modelling of rainfall series as he paern of seasonaliy could be useful for imporan decision making. In addiion, measures should be pu in place o curb human-made aciviies ha are derimenal o he climae since he region is highly vulnerable o he impacs of climae change. Keywords Rainfall, Climae Change, Kalman filer, Kalman Smoohing, Seasonaliy, Sae space model 1. Inroducion Agriculure in Norh-Easern region of Nigeria is predominanly dependen on rainfall. Hence, he oupu from he secor each year is largely deermined by he rainfall seasonal paern, rend and cycles. Weaher as we know is dynamic. Similarly, climae flucuaes or changes over ime and space. According o Nieuwol (1982), he non-saic behaviour in rainfall paerns are in various magniudes ranging from variabiliy hrough flucuaions, rends, and abrup o gradual changes. Some characerisics of rainfall which include is seasonal and diurnal disribuion, inensiy, duraion, onse, cessaion and frequency of rain days all show imporan variaions in respec o ime and places. I is herefore imporan o examine climaic daa o ascerain possible rends and changes in he daa generaing process. Trend could reflec eiher an increase or decrease in he observed phenomenon and may serve as a good indicaor for predicing fuure occurrence. A fair knowledge of he weaher is very necessary, in view of he fac ha farmers, * Corresponding auhor: asemoaomos@yahoo.com (O. J. Asemoa) Published online a hp://journal.sapub.org/saisics Copyrigh 216 Scienific & Academic Publishing. All Righs Reserved power generaion (hydroelecric power generaion), meeorological saions, miliary operaions, safey and emergency agencies such as Naional Emergency Managemen Agency (NEMA) heavily rely on i for heir operaions, among oher socioeconomic aciviies. The high amouns of rainfall which are paricularly received in many elevaed area of he ropics, consiue a reliable basis for he consrucion of many hydro-elecric power saions. There has always been a good deal of ineres in he possibiliy of seasonaliy in rainfall daa. Harvey (1987) poined ou ha he analysis of climaic ime series is essenial for building saisical models o generae synheic hydrologic records, o forecas hydrologic evens, o deec inrinsic sochasic or deerminisic characerisics of hydrologic variables. Assessing he seasonal behaviour of rainfall characerisics and rend is a vial for agriculural pracice in he Norh-Eas saes of Nigeria. In addiion, he ime series analysis of climaic daa provides a basis for asceraining climae change or variabiliy. The Box-Jenkins SARIMA model has been exensively used o model rainfall paerns in Nigeria, see for example, Gulumbe (213), Euk, Moffa and Chims (213) and Marins e al. (214). However, he Box-Jenkins approach is based on he eliminaion of rend and seasonaliy applying seasonal differencing o he series before fiing an
2 24 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach appropriae ARMA model o he daa. Durbin and Koopman (21) noed ha eliminaion of rend and seasonaliy by differencing may pose a problem in applicaions where knowledge of he seasonal paern is needed. Forunaely, modern conrol and sysem heory has shown ha he behaviour of dynamic sysems can be convenienly and succincly described by using he sae space models. Sae space mehod is more general and is based on he modelling of all he observed feaures of he daa. The differen feaures inheren in a series such as rend, seasonal, cycle, explanaory variables and inervenions can be modelled separaely before being pu ogeher in he sae space model. The assumpion of saionariy is no needed in sae space model. Alhough he lieraure on sae space has increased recenly, here is however, no empirical applicaion o modelling rainfall paern in Nigeria. In addiion, using he sae space approach, he naure of seasonaliy presen in he daa will be explicily deermined. I is agains hese backdrops ha his sudy is being proposed. The rainfall received a he synopic saions a Maiduguri and Damauru for hiry-hree years period ( ) are analyzed o evaluae he seasonal behaviour and rend in he monhly daa rainfall. The research is useful in assessing he seasonal behaviour of rainfall characerisics and he rend in he rainfall daa which is a vial requiremen for agriculural pracice in he Norh-Eas saes of Nigeria. I is also inended o provide a basis for asceraining climae change or variabiliy. The res of his paper is organized as follows. In secion 2, sae space models are briefly inroduced, in secion 3, we discuss he modelling mehodology employed in his work. The daa and he empirical resuls are presened and discussed in chaper 4. The final secion concludes he paper. 2. The Model 2.1. Sae Space Model A sae space model consiss of wo equaions: he sae equaion (also called ransiion or sysem equaion) and he observaion equaion (also called measuremen equaion). The observaion equaion expresses he observed variables (daa) as a linear funcion of he sae variable(s) plus noise, while he ransiion equaion describes he evoluion of he sae variables. The ransiion equaion has he form of a firs-order difference equaion. The selecion of componens o include in he sae space model is based on he feaures inheren in he observed ime series. For a series ha have seasonal paerns, he basic srucural model is used, for a srongly rending non-seasonal series; he local rend model is employed. However, for a non-rending series, he local level model is used. Le y denoe an (n 1) vecors of variables observed a ime and be (r 1) unobserved sae vecor. The general sae space represenaion of he dynamics of y is given by: y = AX + H + (1) +1 = F +η (2) The (n x 1) vecor and he (k x 1) vecor η are whie noise: E( ) = R, for =, and oherwise (3) E(η η ) = Q, for =, and oherwise (4) The disurbances are assumed o be uncorrelaed a all lags, ha is; E( η ) = a all and (5) where is k x 1 vecor of unobserved sae variables, H is an n x k marix ha links he observed vecor y o he unobserved, X is an r x 1 vecor of exogenous or predeermined observed variables, A is a marix ha maps he exogenous variables ino he measuremen domain, F is he sae ransiion marix which applies he effec of each sae parameer a ime on he sysem sae a ime +1, R is (n x n) and Q is (k x k) marices of he measuremen equaion variance and ransiion equaion variance respecively. The R variance marices play he same role as in he classical regression model, while he Q variance marices allow he parameers in he sae equaions o evolve over ime. Equaion (1) is known as he observaion equaion and (2) is known as he sae equaion. The sysem of (1) hrough (5) is called sae space models. The essenial difference beween he sae space model and he convenional ARIMA model represenaion is ha in he former, he sae of naure analogous o he regression coefficiens of he laer is no assumed o be consan bu may change wih ime. 3. Modelling Mehodologies 3.1. Sae Space Approach: Local Level Model wih Seasonaliy The local level model or random walk-plus-noise model is a simple form of a linear Gaussian sae space model for modelling series wih no visible rend. The model conains only he level and irregular componens; he single sae (level) variable follows he random walk: y = μ + ε ε ~ NID(, σ 2 ε) μ +1 = μ + ~ NID(, σ 2 ) (6) where ε and are muually uncorrelaed whie-noise processes wih variance σ 2 ε and σ 2. The inerpreaion of his model is ha μ is an (unobservable) local level or mean for he process. The observable y is he underlying process mean conaminaed wih he measuremen error ε. Alhough i has a simple form, i provides he basis for he analysis of imporan real problems in pracical ime series analysis. I exhibis he characerisics srucure of sae space models in which here is a series of unobserved values μ 1 μ n which represens he developmen over ime of he sysem under sudy, ogeher wih a se of observaions y 1,, y n. The aim of he analysis is o sudy he developmen of he sae over ime
3 Inernaional Journal of Saisics and Applicaions 216, 6(4): using he observed values y 1,, y n. However, when a ime series consiss of daily, monhly, or quarerly observaions, he presence of seasonal effecs should be aken ino consideraion. In he sae space framework, seasonaliy can be handled by building he seasonal effecs direcly ino he model. Hence, adding seasonal componens o equaion above yields, y = µ + +, N(, 2 ) µ +1 = µ +, N(, 2 ) +1 = - +1-j + N(, 2 ) (7) where = s-1,..., n. When he seasonal effec is no allowed o change over ime, we require = for all = s -1,..., n. This is done by seing 2 = and (7) is called he local level wih deerminisic seasonal model. When he seasonal effec is allowed o vary over ime, ha is 2 >, he resuling model is called he local level wih sochasic seasonal model. Since he rainfall daa consiss of monhly observaions, he periodiciy of he seasonal is s =12. The sochasic formulaion of he seasonal effec in (7) follows from he sandard dummy variable mehods of modelling seasonal paern. An alernaive way of modelling seasonal effec is by using rigonomeric erms a he seasonal frequencies. Sae space models are esimaed using he Kalman filer. The Kalman filer is a saisical algorihm ha enables cerain compuaions o be carried ou for a model cas in sae space form. However, o obain a more accurae esimae of he sae vecor, he smoohing algorihm is performed. Kalman smoohing provides us wih a more accurae inference on, since i uses more informaion han he filering. Le Y 1 denoe he se of pas observaions y and assuming he condiional 1,, y 1 Y is N( u, p ) where disribuion of given 1 u and p are o be deermined. Assuming ha u and p have been deermined, he celebraed Kalman filer equaions for updaing he above local level model from ime o 1 are given by: u u k p p k k p f 2 1 = +, 1 = (1 - ) +, = /,, (8) 2 = y u-, f p = + for = 1, 2,, n, where denoes he Kalman filer residual or predicion errors, f is is variance and k is he Kalman gain. A random walk like has no naural level and o handle he iniial condiions ( u1, p 1) for he non-saionary model, we employed he exac iniial Kalman filer, (Durbin and Koopman, 21). The Kalman smoohed sae ( ˆ ) and smoohed sae variance ( V ) can be calculaed by he following backward recursions: 1 2 ˆ = u + pr 1, r 1 = f + lr, l = 1 k / f, n,,1 N =, for,,1 V p p N, N f l N, n,,1 (9) wih r n and n n. The unknown variance parameers in he sae space model are esimaed by he maximum likelihood esimaion via he Kalman filer predicion error decomposiion iniialized wih he exac iniial Kalman filer. Harvey and Peers (199) suggesed concenraion of he log likelihood when he variance parameers display difficul esimaion problems, as his helps o improve he behavior of difficul esimaion. Diagnosic checking in he sae space models are based on he hree assumpions concerning he residuals of he analysis. The residuals should saisfy hese hree properies, in order of imporance; independence, homoscedasiciy and normaliy. These assumpions are checked using he following es saisic; The assumpion of independence of he residuals can be checked wih he Ljung-Box saisic defined as; Q (k) = n(n + 2) k r2 l=1 n l 2 (k-w+1) (1) For lags l = 1,...,k. The number of diffuse iniial sae values which need o be esimaed for he level and seasonal componens in (7) corresponds o k, r l denoes he residual auocorrelaion for lag l and w is he number of hyperparameers (i.e. disurbance variances). The second mos imporan assumpion is he homoscedasiciy of he residuals. This is checked using he following es saisic; H(h) = n 2 =n h +1 ε =d+h ε2 =d+1 F (h, h) (11) where d is he number of diffuse iniial elemens, and h is he neares ineger o (n- d) /3. The leas imporan assumpion is ha he residuals are normally disribued. This assumpion can be checked wih he following es saisic; N = n s 6 + (k 3) df (12)
4 26 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach where s denoes he skewness of he residuals, and k is he kurosis. In he sae space models, he sandardized smoohed disurbances are useful for deecion of possible ouliers and srucural breaks. The deecion of srucural break using he cumulaive sum (CUSUM) es is considered in his work. 4. Daa and Empirical Resuls 4.1. The Daa The monhly rainfall daa for wo Norh-Easern areas (Maiduguri and Yobe, see Annexure I) from January, 1981 o December 213 are examined in his sudy. The monhly rainfall daa measured in millimeer is obained from he Nigeria Meeorological Agency (NIMET), Lagos sae office. The plos of he rainfall series are presened in Figure 1 and Figure 2 for Maiduguri and Damauru respecively. 3 Maiduguri Rainfall ( ) Maiduguri Rainfall wih Time Lines for Years Figure 1. Time Series Plo of Maiduguri Rainfall 3 Yobe Rainfall ( ) Yobe Rainfall wih Time Lines for Years Figure 2. Time Series Plo of Damauru Rainfall
5 Inernaional Journal of Saisics and Applicaions 216, 6(4): From figure 1 he rainfall series flucuaes over he years bu had he highes spike in 1999 and he lowes in 1983 and figure 2 also indicaes ha he rainfall had is peak in 212 and he lowes in The descripive saisics of he subsamples of boh series are presened in able 1 and 2. Table 1 and 2 indicae ha he subsample means and variance are no he same over ime, which is an indicaion ha he subsample means and variance are no consan. For example, he subsample mean for Damauru beween 1981:1 o 1991:1 is 28.1 while for 1992:1 o 21:1 and 22: 1 o 213:12 are and respecively. Hence, he means varies across he samples. Thus, he sae space model ha accommodaes non-saionary feaures by represening he level of he series as a random walk process, since random walk process is non-saionary, would be appropriae for modelling he series. Table 1. Descripive Saisics of Maiduguri Rainfall Table 2. Descripive Saisics of Damauru Rainfall
6 28 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach 4.2. Esimaion Resuls and Discussion The selecion of componens o be included in a sae space model is based on he characerisics of he observed series. Since seasonaliy is normally presen in a monhly ime series daa, we employed he local level wih sochasic seasonal and local level wih deerminisic seasonal models described in secion 3 o he Maiduguri and Damauru original series. Firs, using he daa, we esimae he unknown variance parameers (hyperparameers) of he models using maximum likelihood mehod. This is maximized using he BFGS (Broyden-Flecher-Goldfarb-Shannon) opimizaion mehod. The esimaion resuls for he local level model wih sochasic seasonal is presened below. Table 3. Esimaion Variance for Local Level Model wih Sochasic Seasonal for Maiduguri Rainfall series (1981:1 213:12) Noe: SIGSQEPS, SIGSQETA and SIGSQOMEGA denoe esimaes 2, 2 and 2 respecively. Table 4. Esimaion Variance for Local Level Model wih Sochasic Seasonal for Damauru Rainfall series (1981:1 213:12) Noe: SIGSQEPS, SIGSQETA and SIGSQOMEGA denoe esimaes 2, 2 and 2 respecively. The esimaion resuls in able 3 and 4 indicaes ha he hyperparameers (disurbance variances) of he measuremen and seasonal componen are highly saisically significan; however, he esimaed hyperparameers for he level equaions is no saisically significan. This indicaes ha any seasonal paern in he observed ime series changes over he years. Also, here are 396 observaions in boh series; however, he esimaion is done using only he final 384 observaions. This is because 12 diffuse iniial sae values are esimaed (11 for he seasonal componens and 1 for he local level componens). We proceed ino performing he Kalman filering and kalman smoohing using he esimaed hyperparameers. The resuls of he Kalman filer esimaes for Maiduguri rainfall series is presened in figure 3 and 4 while figure 5 and 6 presen ha of Damauru rainfall series respecively.
7 Inernaional Journal of Saisics and Applicaions 216, 6(4): Filered Lev el Filered Seasonal Fied Values Kalm an Filer Oupu for Local level + Sochasic Seasonal Figure 3. Kalman Filer Oupu for local level wih sochasic seasonal for Maiduguri series 9 6 Filered Level Variance 3 Filered Seasonal Variance Predicion Errors Kalman Filer Variances for Local level + Sochasic Seasonal Figure 4. Kalman Filer Oupu for local level wih sochasic seasonal for Maiduguri series
8 21 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach 42.5 Filered Level Filered Seasonal Fied Values Kalman Filer Oupu f or Local lev el + Sochasic Seasonal Figure 5. Kalman Filer Oupu for local level wih sochasic seasonal for Damauru series Filered Level Variance Filered Seasonal Variance Predicion Errors Kalman Filer Variances for Local level + Sochasic Seasonal Figure 6. Kalman Filer Oupu for local level wih sochasic seasonal for Damauru series
9 Inernaional Journal of Saisics and Applicaions 216, 6(4): Smoohed Level Smoohed Seasonal 1-2 Smoohed Fied Values 1 - Kalman Smoohed Oupu for Local level + Sochasic Seasonal Figure 7. Kalman Smoohed Oupu for local level wih sochasic seasonal for Maiduguri series Smoohed Level Variance Smoohed Seasonal Variance Smoohed Predicion Errors Kalman Smoohed Variances f or Local lev el + Sochasic Seasonal Figure 8. Kalman Smoohed Oupu for local level wih sochasic seasonal for Maiduguri series
10 212 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach Smoohed Level Smoohed Seasonal Smoohed Fied Values Kalman Smoohed Oupu f or Local level + Sochasic Seasonal Figure 9. Kalman Smoohed Oupu for local level wih sochasic seasonal for Damauru series Smoohed Level Variance Smoohed Seasonal Variance Smoohed Predicion Errors Kalman Smoohed Variances for Local level + Sochasic Seasonal Figure 1. Kalman Smoohed Oupu for local level wih sochasic seasonal for Damauru series
11 Inernaional Journal of Saisics and Applicaions 216, 6(4): Figure 3 o 6 presen graphically he dynamic evoluion of he level, seasonal componens and he fied values obained by he Kalman filer ogeher wih heir variances and he predicion errors (residuals). The evoluion of he wo Norh-Easern regions under sudy is refleced by he esimaed level componen and is presened in he upper graph of figure 3 and 5. The plos indicae ha he period of highes level of rainfall in Maiduguri occurred in he 26 and he lowes level of rainfall occurred in he From figure 5, he plo also indicaes ha he period of he highes level of rainfall in Damauru occurred in he 2, while he lowes level of rainfall occurred beween 1988 and One obvious feaures of figure 4 is ha, he Kalman filered sae variances converges o zero value, which implies ha here is no variabiliy, while in figure 6, he Kalman filered sae variance converges o a consan value as he sample size increases which empirically confirms ha he fied local level model has a seady sae soluion. Figure 7 o 1 presen he resuls of he Kalman smoohing recursion esimaes of he level, seasonal and he fied values of he series ogeher wih he sae variances of he level, seasonal componen and he smoohed predicion errors respecively. On comparing he graphs of he Kalman filered level and he smoohed level of he wo Norheas saes in figure 3 o 5 and 7 o 9 respecively, i is obvious ha figure 7 o 9 is smooher han ha of figure 3 o 5. In addiion, figure 7 o 9 reveal ha he seasonal paern in he Maiduguri and Damauru series have been relaively consan over he years. In order o deec any sysemaic and haphazard srucural breaks, we employed he cumulaive sum (CUSUM) and cumulaive sum squares (CUSUMSQ) inroduced by Brown e al. (19) o he residuals of he fied model. The resuls of he CUSUM es are displayed in figure 11 and 12. Figure 11 indicaes ha here was a srucural break around Similarly, figure indicaes he possibiliy of a srucural break in he year Sig Level CUSUM es CUSUMSQ es CUSUM Tess Figure 11. The CUSUM and CUSUMSQ Srucural Break es for Maiduguri Rainfall.
12 214 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach 3 Sig Level CUSUM es CUSUMSQ es CUSUM Tess Figure 12. The CUSUM and CUSUMSQ Srucural Break es for Damauru Rainfall Table 5. Diagnosics Resuls for Local Level Model wih Sochasic Seasonal for Maiduguri Series Table 6. Diagnosics Resuls for Local Level Model wih Sochasic Seasonal for Damauru Series
13 Inernaional Journal of Saisics and Applicaions 216, 6(4): Table 5 indicaes ha he diagnosic ess for independence, homoscedasiciy, and normaliy of he residuals for he fied Maiduguri model are all saisfacory. These ess indicae ha he residuals saisfy all of he assumpions of he models since he p-value associaed wih all he ess are insignifican a he convenional.5 significance level. Also, from able 6, he diagnosic ess for independence and homoscedasiciy of he residuals are saisfacory for Damauru fied model, while ha of normaliy is no saisfacory, which suggess ha he residuals saisfy he wo mos imporan assumpions of he models as discussed in secion 3. However, he residuals are higher a he beginning and end of he sample, as heoreically expeced, since he smoohed saes are calculaed by a backwards recursions. Hence, he uncerainy in he esimaion is higher a he beginning of he backward recursions, unlike he Kalman filering ha uses a forward recursion. We now presen he resuls of analysis of Maiduguri and Damauru rainfall ime series wih a local level model wih a deerminisic seasonal. Table 7. Esimaion Resuls for Local Level Model wih Deerminisic Seasonal for Maiduguri Rainfall Series (1981:1-213:12) Noe: SIGSQEPS and SIGSQETA denoe esimaes 2 and 2 respecively, 2 is fixed a zero. Table 8. Esimaion Resuls for Local Level Model wih Deerminisic Seasonal for Damauru Rainfall Series (1981:1-213:12) Noe: SIGSQEPS and SIGSQETA denoe esimaes 2 and 2 respecively, 2 is fixed a zero. The esimaion resuls display above shows ha he esimaed hyperparameers (disurbance variances) of he measuremen equaion is significan while ha of he level equaion is no significan. Also, here are 396 observaions in our series; however, he esimaion is done using only he final 384 observaions. This is because 12 diffuse iniial sae values are esimaed (11 for he seasonal componens and 1 for he local level componens). We perform he Kalman filering and smoohing based on hese wo esimaes. We presen he resuls of he Kalman filer esimaes of he local level model wih deerminisic seasonal for Maiduguri and Damauru in figure 13 o 16 and Kalman smoohed esimaes of he local level model wih deerminisic seasonal in figure 16 and 19. Figures 13 and 16 presen he oupu of he Kalman filering of he local level model wih deerminisic seasonaliy for Maiduguri and Damauru respecively. The oupu is very similar o he oupu of he local level model wih sochasic seasonal (his is because he variance is small and insignifican), he evoluion of Maiduguri and Damauru rainfall is refleced by he esimaed level componen and is presened in he upper graph of figure 13 and 14. The plos also indicaes ha he period of highes level of rainfall in Maiduguri and Damauru occurred in 26 and 2 respecively, while he lowes level occurred in 1986 and respecively. Figure 14 also reveals ha he Kalman filered sae variances converges o zero, while he filered seasonal variance converges o a consan value. From figure 16, he filered level variance converges o consan values as he sample size increases which empirically confirms ha he local level model has a seady sae soluion.
14 216 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach Filered Lev el Filered Seasonal Fied Values Kalman Filer Oupu for Local level + Deerminisic Seasonal Figure 13. Kalman Filer Oupu for local level wih deerminisic seasonal for Maiduguri series Filered Lev el Variance Filered Seasonal Variance Predicion Errors Kalman Filer Oupu for Local level + Deerminisic Seasonal Figure 14. Kalman Filer Oupu for local level wih deerminisic seasonal for Maiduguri series
15 Inernaional Journal of Saisics and Applicaions 216, 6(4): Filered Level Filered Seasonal 1-1 Fied Values 1 - Kalman Filer Oupu for Local level + Deerminisic Seasonal Figure 15. Kalman Filer Oupu for local level wih deerminisic seasonal for Damauru series 6 Filered Lev el Variance Filered Seasonal Variance Predicion Errors Kalman Filer Oupu f or Local lev el + Deerminisic Seasonal Figure 16. Kalman Filer Oupu for local level wih deerminisic seasonal for Damauru series
16 218 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach Figures 17 o 2 presen he oupu of he Kalman smoohing recursion esimaes of he level, seasonal and he fied values of he series ogeher wih he sae variances of he level and seasonal componen and he smoohed predicion errors for Maiduguri and Damauru series. Comparing he graphs of he Kalman filered level and he smoohed level in figure 13 and 15 and figure 17and 19, we see ha he graph in figure 17 and 19 is smooher han ha of figure 13 and15 for boh saes. However, he consan seasonal paern in he series is clearly apparen in figure 18 and Smoohed Level Smoohed Seasonal 1 - Smoohed Fied Values Kalman Smoohed Oupu f or Local lev el + Deerminisic Seasonal Figure 17. Kalman Smoohed Oupu for local level wih deerminisic seasonal for Maiduguri series Table 9. Diagnosics Resuls for Local Level Model wih Deerminisic Seasonal for Maiduguri Rainfall Series Table 1. Diagnosics Resuls for Local Level Model wih Deerminisic Seasonal for Damauru Rainfall Series
17 Inernaional Journal of Saisics and Applicaions 216, 6(4): Smoohed Level Variance Smoohed Seasonal Variance Smoohed Predicion Errors Kalman Smoohed Variances for Local level + Deerminisic Seasonal Figure 18. Kalman Smoohed Oupu for local level wih deerminisic seasonal for Maiduguri series 4 Smoohed Lev el Smoohed Seasonal Smoohed Fied Values Kalman Smoohed Oupu for Local level + Deerminisic Seasonal Figure 19. Kalman Smoohed Oupu for local level wih deerminisic seasonal for Damauru series
18 22 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach 14 Smoohed Level Variance Smoohed Seasonal Variance Smoohed Predicion Errors Kalman Smoohed Variances for Local level + Deerminisic Seasonal Figure 2. Kalman Smoohed Oupu for local level wih deerminisic seasonal for Damauru series From able 8 and 1, he resuls of he diagnosic ess for he residuals of he local level model wih deerminisic seasonal are again saisfacory excep for he normaliy of Damauru. From able 9, he assumpion of independence, homoscedasiciy and normaliy are saisfied a he convenional level while able 1 indicaes ha he assumpion of normaliy is no saisfied a convenional significance level. From he wo compeing model ha is; local level sochasic and local level deerminisic model, he Akaike Informaion Crierion (AIC) and he Bayesian Informaion Crierion (SIC) of he wo models are examined o obain he parsimonious model. Using he informaion crieria approach, models ha yield smaller values for he crierion are preferred, and regarded as bes fiing model. From able 5 and 6, he AIC and BIC for he local level model wih sochasic seasonal are 9.89, 9.21 and 9.92, 9.24, for Maiduguri and Damauru respecively, while he AIC and BIC for he local level model wih deerminisic seasonal displayed in able 9 and 1 are 9.88, 9.21 and 9.9, 9.23 for Maiduguri and Damauru respecively. Hence, he local level model wih deerminisic seasonal is slighly beer han he model wih sochasic seasonal componen. In addiion, he log-likelihood values of he wo models for he wo saes are almos idenical , and , for he local level model wih sochasic seasonal and he local level model wih deerminisic seasonal respecively. Hence, he improved fi of he local level model wih deerminisic model can compleely be aribued o is greaer parsimony. Commandeur and Koopman (27) poined ou ha, in sae space modelling, a small and insignifican sae disurbance variance indicaes ha he corresponding sae componen may as well be reaed as a deerminisic effec, resuling in a more parsimonious model. Therefore, he local level model wih deerminisic seasonal is able o model he dynamic feaures
19 Inernaional Journal of Saisics and Applicaions 216, 6(4): in he Maiduguri and Damauru rainfall ime series. 5. Conclusions The variabiliy in elemens of climae such as rainfall and emperaure exposes he counry o he negaive impac of climae change such as erraic rainfall, rise in emperaure, deserificaion, low agriculural yield, drying up of waer bodies, and sea level rise. This paper analysed he seasonal paern of rainfall in Maiduguri and Damauru in he sae space framework. We employ he local level model wih deerminisic and sochasic seasonal o modelling he monhly rainfall of he wo saes. The AIC and BIC of he wo sae space models sugges ha he local level model wih deerminisic seasonal provide a beer fi o he daa han he model wih sochasic seasonal. The deecion of deerminisic seasonal in he wo saes implies ha he rainfall fall paerns have lile variabiliy or indicaion of climae change as regards is rainfall elemen. In addiion, he CUSUM es indicaes he presence of srucural breaks in 1998 and 199 for Maiduguri and Damauru respecively. This implies ha here was abrup change in he rainfall level in 1998 for Maiduguri area and in 199 for Damauru area. We, herefore, recommend ha seasonaliy should be explicily included in he modelling of seasonal ime series daa as he paern of seasonaliy could be useful for imporan decision making. These echniques can be adoped o he analysis of ime series drawn from oher domains. In addiion, measures should be pu in place o curb human-made aciviies ha are derimenal o he climae since he region is highly vulnerable o he impacs of climae change. All compuaions performed in his sudy are done using he RATS economeric ime series sofware. Annexure I. Geographical Map of he Sudy Area
20 222 O. J. Asemoa e al.: Modelling Seasonal Behaviour of Rainfall in Norheas Nigeria. A Sae Space Approach [7] Jacques, J.F. and Koopman, S.J. (27). An Inroducion o Sae Space Analysis. Unied Sae: Oxford Universiy Press. REFERENCES [1] Ampaw, E. M. e al. (213) Time Series Modelling of Rainfall in New Juaben Municipaliy of he Easern Region of Ghana. Inernaional Journal of Business and Social Science. (4), p [2] Brown, R.L., Durbin, J., & Evans, J.M. (19). Techniques for esing he consancy of regression relaionships over ime. Journal of he Royal Saisical sociey, series B, 37, [3] Dike, I.J. and Jibasen, D. (1997) Saisical Modelling Of Rainfall in Some Nigerian Ciies. Unpublished aricle, p [4] Dikko, H. G., David, I. J. and Bakari H.R.(213) Modeling he Disribuion of Rainfall Inensiy using Quarerly Daa. IOSR Journal of Mahemaics. 9, p [5] Durbin, J. and Koopman, S. (21) Time Series Analysis by Sae Space Mehods. Unied Sae: Oxford Universiy Press. [6] Igwenagu, C. M (215) Trend Analysis of Rainfall Paern in Enugu Sae, Nigeria. European Journal of Saisics and Probabiliy. 3 (3), p [8] Kim, C.J. and Nelson, C.R. (1999). Sae-Space Models wih Regime Swiching. Cambridge: MIT Press. [9] Koopman, S. and Durbin, J. (214). Time Series Analysis by Sae Space Mehods, 2 nd Ediion, Unied Sae: Oxford Universiy Press. [1] Peer, M.W. (2). Modelling Seasonaliy and Trends in Daily Rainfall Daa. Unpublished aricle. p [11] Ramana, R.V., Krishna, B. and Kumar, S.R. (213) Monhly Rainfall Predicion Using Wavele [12] Neural Nework Analysis. Journal of Waer Resources Managemen. 27, p [13] Wee, P.MJ. and Shian, M. (213). Modelling Rainfall Duraion And Severiy Using Copula. SrinLankan Journal of Applied Saisics, 14-1, p [14] Wes, M. and Harrison, J. (1997). Bayesian Forecasing and Dynamic Models, 2nd Ediion. Springer-Verlag, New York. [15] Yusof, F.and Kane, I.L. (212) Modelling Monhly Rainfall Time Series Using Es Sae Space and Sarima Models. Inernaional Journal of Curren Research. 4 (9), p
State-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 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 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 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 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 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 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 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 informationLinear Gaussian State Space Models
Linear Gaussian Sae Space Models Srucural Time Series Models Level and Trend Models Basic Srucural Model (BSM Dynamic Linear Models Sae Space Model Represenaion Level, Trend, and Seasonal Models Time Varying
More informationExponential Weighted Moving Average (EWMA) Chart Under The Assumption of Moderateness And Its 3 Control Limits
DOI: 0.545/mjis.07.5009 Exponenial Weighed Moving Average (EWMA) Char Under The Assumpion of Moderaeness And Is 3 Conrol Limis KALPESH S TAILOR Assisan Professor, Deparmen of Saisics, M. K. Bhavnagar Universiy,
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 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 informationGeorey E. Hinton. University oftoronto. Technical Report CRG-TR February 22, Abstract
Parameer Esimaion for Linear Dynamical Sysems Zoubin Ghahramani Georey E. Hinon Deparmen of Compuer Science Universiy oftorono 6 King's College Road Torono, Canada M5S A4 Email: zoubin@cs.orono.edu Technical
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 informationSTATE-SPACE MODELLING. A mass balance across the tank gives:
B. Lennox and N.F. Thornhill, 9, Sae Space Modelling, IChemE Process Managemen and Conrol Subjec Group Newsleer STE-SPACE MODELLING Inroducion: Over he pas decade or so here has been an ever increasing
More informationRecursive Least-Squares Fixed-Interval Smoother Using Covariance Information based on Innovation Approach in Linear Continuous Stochastic Systems
8 Froniers in Signal Processing, Vol. 1, No. 1, July 217 hps://dx.doi.org/1.2266/fsp.217.112 Recursive Leas-Squares Fixed-Inerval Smooher Using Covariance Informaion based on Innovaion Approach in Linear
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 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 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 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 informationModeling Rainfall in Dhaka Division of Bangladesh Using Time Series Analysis.
Journal of Mahemaical Modelling and Applicaion 01, Vol. 1, No.5, 67-73 ISSN: 178-43 67 Modeling Rainfall in Dhaka Division of Bangladesh Using Time Series Analysis. Md. Mahsin Insiue of Saisical Research
More informationUse of Unobserved Components Model for Forecasting Non-stationary Time Series: A Case of Annual National Coconut Production in Sri Lanka
Tropical Agriculural Research Vol. 5 (4): 53 531 (014) Use of Unobserved Componens Model for Forecasing Non-saionary Time Series: A Case of Annual Naional Coconu Producion in Sri Lanka N.K.K. Brinha, S.
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 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 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 informationFITTING OF A PARTIALLY REPARAMETERIZED GOMPERTZ MODEL TO BROILER DATA
FITTING OF A PARTIALLY REPARAMETERIZED GOMPERTZ MODEL TO BROILER DATA N. Okendro Singh Associae Professor (Ag. Sa.), College of Agriculure, Cenral Agriculural Universiy, Iroisemba 795 004, Imphal, Manipur
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 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 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 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 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 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 informationApplication of a Stochastic-Fuzzy Approach to Modeling Optimal Discrete Time Dynamical Systems by Using Large Scale Data Processing
Applicaion of a Sochasic-Fuzzy Approach o Modeling Opimal Discree Time Dynamical Sysems by Using Large Scale Daa Processing AA WALASZE-BABISZEWSA Deparmen of Compuer Engineering Opole Universiy of Technology
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 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 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 informationSUPPLEMENTARY INFORMATION
SUPPLEMENTARY INFORMATION DOI: 0.038/NCLIMATE893 Temporal resoluion and DICE * Supplemenal Informaion Alex L. Maren and Sephen C. Newbold Naional Cener for Environmenal Economics, US Environmenal Proecion
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 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 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 informationhen found from Bayes rule. Specically, he prior disribuion is given by p( ) = N( ; ^ ; r ) (.3) where r is he prior variance (we add on he random drif
Chaper Kalman Filers. Inroducion We describe Bayesian Learning for sequenial esimaion of parameers (eg. means, AR coeciens). The updae procedures are known as Kalman Filers. We show how Dynamic Linear
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 informationStochastic Model for Cancer Cell Growth through Single Forward Mutation
Journal of Modern Applied Saisical Mehods Volume 16 Issue 1 Aricle 31 5-1-2017 Sochasic Model for Cancer Cell Growh hrough Single Forward Muaion Jayabharahiraj Jayabalan Pondicherry Universiy, jayabharahi8@gmail.com
More informationIn this paper the innovations state space models (ETS) are used in series with:
Time series models for differen seasonal paerns Blaconá, M.T, Andreozzi*, L. and Magnano, L. Naional Universiy of Rosario, (*)CONICET - Argenina Absrac In his paper Innovaions Sae Space Models (ETS) are
More informationReferences are appeared in the last slide. Last update: (1393/08/19)
SYSEM IDEIFICAIO Ali Karimpour Associae Professor Ferdowsi Universi of Mashhad References are appeared in he las slide. Las updae: 0..204 393/08/9 Lecure 5 lecure 5 Parameer Esimaion Mehods opics o be
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 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 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 information20. Applications of the Genetic-Drift Model
0. Applicaions of he Geneic-Drif Model 1) Deermining he probabiliy of forming any paricular combinaion of genoypes in he nex generaion: Example: If he parenal allele frequencies are p 0 = 0.35 and q 0
More informationModal identification of structures from roving input data by means of maximum likelihood estimation of the state space model
Modal idenificaion of srucures from roving inpu daa by means of maximum likelihood esimaion of he sae space model J. Cara, J. Juan, E. Alarcón Absrac The usual way o perform a forced vibraion es is o fix
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 informationAir Traffic Forecast Empirical Research Based on the MCMC Method
Compuer and Informaion Science; Vol. 5, No. 5; 0 ISSN 93-8989 E-ISSN 93-8997 Published by Canadian Cener of Science and Educaion Air Traffic Forecas Empirical Research Based on he MCMC Mehod Jian-bo Wang,
More informationInternational Parity Relations between Poland and Germany: A Cointegrated VAR Approach
Research Seminar a he Deparmen of Economics, Warsaw Universiy Warsaw, 15 January 2008 Inernaional Pariy Relaions beween Poland and Germany: A Coinegraed VAR Approach Agnieszka Sążka Naional Bank of Poland
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 informationNature Neuroscience: doi: /nn Supplementary Figure 1. Spike-count autocorrelations in time.
Supplemenary Figure 1 Spike-coun auocorrelaions in ime. Normalized auocorrelaion marices are shown for each area in a daase. The marix shows he mean correlaion of he spike coun in each ime bin wih he spike
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 informationWATER LEVEL TRACKING WITH CONDENSATION ALGORITHM
WATER LEVEL TRACKING WITH CONDENSATION ALGORITHM Shinsuke KOBAYASHI, Shogo MURAMATSU, Hisakazu KIKUCHI, Masahiro IWAHASHI Dep. of Elecrical and Elecronic Eng., Niigaa Universiy, 8050 2-no-cho Igarashi,
More informationAn introduction to the theory of SDDP algorithm
An inroducion o he heory of SDDP algorihm V. Leclère (ENPC) Augus 1, 2014 V. Leclère Inroducion o SDDP Augus 1, 2014 1 / 21 Inroducion Large scale sochasic problem are hard o solve. Two ways of aacking
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 information0.1 MAXIMUM LIKELIHOOD ESTIMATION EXPLAINED
0.1 MAXIMUM LIKELIHOOD ESTIMATIO EXPLAIED Maximum likelihood esimaion is a bes-fi saisical mehod for he esimaion of he values of he parameers of a sysem, based on a se of observaions of a random variable
More informationInstitute for Mathematical Methods in Economics. University of Technology Vienna. Singapore, May Manfred Deistler
MULTIVARIATE TIME SERIES ANALYSIS AND FORECASTING Manfred Deisler E O S Economerics and Sysems Theory Insiue for Mahemaical Mehods in Economics Universiy of Technology Vienna Singapore, May 2004 Inroducion
More informationSummer Term Albert-Ludwigs-Universität Freiburg Empirische Forschung und Okonometrie. Time Series Analysis
Summer Term 2009 Alber-Ludwigs-Universiä Freiburg Empirische Forschung und Okonomerie Time Series Analysis Classical Time Series Models Time Series Analysis Dr. Sevap Kesel 2 Componens Hourly earnings:
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 informationMonitoring and data filtering II. Dynamic Linear Models
Ouline Monioring and daa filering II. Dynamic Linear Models (Wes and Harrison, chaper 2 Updaing equaions: Kalman Filer Discoun facor as an aid o choose W Incorporae exernal informaion: Inervenion General
More informationAn recursive analytical technique to estimate time dependent physical parameters in the presence of noise processes
WHAT IS A KALMAN FILTER An recursive analyical echnique o esimae ime dependen physical parameers in he presence of noise processes Example of a ime and frequency applicaion: Offse beween wo clocks PREDICTORS,
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 informationCHAPTER 10 VALIDATION OF TEST WITH ARTIFICAL NEURAL NETWORK
175 CHAPTER 10 VALIDATION OF TEST WITH ARTIFICAL NEURAL NETWORK 10.1 INTRODUCTION Amongs he research work performed, he bes resuls of experimenal work are validaed wih Arificial Neural Nework. From he
More informationImo Udo Moffat Department of Mathematics/Statistics, University of Uyo, Nigeria
Inernaional Journals of Advanced Research in Compuer Science and Sofware Engineering ISSN: 2277-128 (Volume-7, Issue-8) a Research Aricle Augus 2017 Applicaion of Inerruped Time Series Modelling o Prime
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 informationArticle from. Predictive Analytics and Futurism. July 2016 Issue 13
Aricle from Predicive Analyics and Fuurism July 6 Issue An Inroducion o Incremenal Learning By Qiang Wu and Dave Snell Machine learning provides useful ools for predicive analyics The ypical machine learning
More informationSliding Mode Controller for Unstable Systems
S. SIVARAMAKRISHNAN e al., Sliding Mode Conroller for Unsable Sysems, Chem. Biochem. Eng. Q. 22 (1) 41 47 (28) 41 Sliding Mode Conroller for Unsable Sysems S. Sivaramakrishnan, A. K. Tangirala, and M.
More informationTime series model fitting via Kalman smoothing and EM estimation in TimeModels.jl
Time series model fiing via Kalman smoohing and EM esimaion in TimeModels.jl Gord Sephen Las updaed: January 206 Conens Inroducion 2. Moivaion and Acknowledgemens....................... 2.2 Noaion......................................
More informationA new flexible Weibull distribution
Communicaions for Saisical Applicaions and Mehods 2016, Vol. 23, No. 5, 399 409 hp://dx.doi.org/10.5351/csam.2016.23.5.399 Prin ISSN 2287-7843 / Online ISSN 2383-4757 A new flexible Weibull disribuion
More informationTourism forecasting using conditional volatility models
Tourism forecasing using condiional volailiy models ABSTRACT Condiional volailiy models are used in ourism demand sudies o model he effecs of shocks on demand volailiy, which arise from changes in poliical,
More informationFrequency independent automatic input variable selection for neural networks for forecasting
Universiä Hamburg Insiu für Wirschafsinformaik Prof. Dr. D.B. Preßmar Frequency independen auomaic inpu variable selecion for neural neworks for forecasing Nikolaos Kourenzes Sven F. Crone LUMS Deparmen
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 informationExponentially Weighted Moving Average (EWMA) Chart Based on Six Delta Initiatives
hps://doi.org/0.545/mjis.08.600 Exponenially Weighed Moving Average (EWMA) Char Based on Six Dela Iniiaives KALPESH S. TAILOR Deparmen of Saisics, M. K. Bhavnagar Universiy, Bhavnagar-36400 E-mail: kalpesh_lr@yahoo.co.in
More information2.160 System Identification, Estimation, and Learning. Lecture Notes No. 8. March 6, 2006
2.160 Sysem Idenificaion, Esimaion, and Learning Lecure Noes No. 8 March 6, 2006 4.9 Eended Kalman Filer In many pracical problems, he process dynamics are nonlinear. w Process Dynamics v y u Model (Linearized)
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 informationRecursive Estimation and Identification of Time-Varying Long- Term Fading Channels
Recursive Esimaion and Idenificaion of ime-varying Long- erm Fading Channels Mohammed M. Olama, Kiran K. Jaladhi, Seddi M. Djouadi, and Charalambos D. Charalambous 2 Universiy of ennessee Deparmen of Elecrical
More informationMathematical Theory and Modeling ISSN (Paper) ISSN (Online) Vol 3, No.3, 2013
Mahemaical Theory and Modeling ISSN -580 (Paper) ISSN 5-05 (Online) Vol, No., 0 www.iise.org The ffec of Inverse Transformaion on he Uni Mean and Consan Variance Assumpions of a Muliplicaive rror Model
More informationOn a Discrete-In-Time Order Level Inventory Model for Items with Random Deterioration
Journal of Agriculure and Life Sciences Vol., No. ; June 4 On a Discree-In-Time Order Level Invenory Model for Iems wih Random Deerioraion Dr Biswaranjan Mandal Associae Professor of Mahemaics Acharya
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 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 informationChapter 2. Models, Censoring, and Likelihood for Failure-Time Data
Chaper 2 Models, Censoring, and Likelihood for Failure-Time Daa William Q. Meeker and Luis A. Escobar Iowa Sae Universiy and Louisiana Sae Universiy Copyrigh 1998-2008 W. Q. Meeker and L. A. Escobar. Based
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 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 informationThe expectation value of the field operator.
The expecaion value of he field operaor. Dan Solomon Universiy of Illinois Chicago, IL dsolom@uic.edu June, 04 Absrac. Much of he mahemaical developmen of quanum field heory has been in suppor of deermining
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 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 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 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 informationEnergy Storage Benchmark Problems
Energy Sorage Benchmark Problems Daniel F. Salas 1,3, Warren B. Powell 2,3 1 Deparmen of Chemical & Biological Engineering 2 Deparmen of Operaions Research & Financial Engineering 3 Princeon Laboraory
More informationMean Reversion of Balance of Payments GEvidence from Sequential Trend Break Unit Root Tests. Abstract
Mean Reversion of Balance of Paymens GEvidence from Sequenial Trend Brea Uni Roo Tess Mei-Yin Lin Deparmen of Economics, Shih Hsin Universiy Jue-Shyan Wang Deparmen of Public Finance, Naional Chengchi
More information"FORECASTING OF THE RAINFALL AND THE DISCHARGE OF THE NAMORONA RIVER IN VOHIPARARA AND FFT ANALYSES OF THESE DATA
"FORECASTING OF THE RAINFALL AND THE DISCHARGE OF THE NAMORONA RIVER IN VOHIPARARA AND FFT ANALYSES OF THESE DATA Andry Tefinanahary RABENJA, Adolphe RATIARISON and Jean Marc RABEHARISOA Suspensions Rheology
More informationEvaluation of Mean Time to System Failure of a Repairable 3-out-of-4 System with Online Preventive Maintenance
American Journal of Applied Mahemaics and Saisics, 0, Vol., No., 9- Available online a hp://pubs.sciepub.com/ajams/// Science and Educaion Publishing DOI:0.69/ajams--- Evaluaion of Mean Time o Sysem Failure
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 informationOn Multicomponent System Reliability with Microshocks - Microdamages Type of Components Interaction
On Mulicomponen Sysem Reliabiliy wih Microshocks - Microdamages Type of Componens Ineracion Jerzy K. Filus, and Lidia Z. Filus Absrac Consider a wo componen parallel sysem. The defined new sochasic dependences
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 informationStability and Bifurcation in a Neural Network Model with Two Delays
Inernaional Mahemaical Forum, Vol. 6, 11, no. 35, 175-1731 Sabiliy and Bifurcaion in a Neural Nework Model wih Two Delays GuangPing Hu and XiaoLing Li School of Mahemaics and Physics, Nanjing Universiy
More information