The Insurance Risk in the SST and in Solvency II: Modeling and Parameter Estimators
|
|
- Kristian Hill
- 6 years ago
- Views:
Transcription
1 The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators ASTIN Colloquum 1-4 June 009, Helsnk Alos Gsler
2 Introducton SST and Solvency II common goal: to nstall a rsk based solvency regulaton solvency captal requred (SCR) should depend on the rsks a company has on ts book SST 004: standard SST model developed and frst feld test 008: all Swss companes have to calculate the SST fgures 011: SST SCR wll be n force Solvency II 007: SII Framework Drectve Proposal adopted by the EU Commsson 008: 4 th quanttatve mpact study 01: "orgnal" schedule to put the regulaton nto force schedule under dscusson Subject of ths presentaton: non-lfe nsurance rsk modelng and parameter estmators ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
3 The Insurance Rsk Non-Lfe Insurance Rsk non-lfe nsurance rsk = next years techncal result CY PY TR = P K C C E ( P K E C C E C ) C expected techncal result CY CY CY PY where P K CY C PY C = earned premum, = admnstratve costs, = total clam amount current year (CY), = total clam amount prevous years (PY) = CDR (CDR = clams development result) segmented nto lnes of busness (lob) =1,,...,I ; 3 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
4 Modelng n SST: Insurance Rsk CY clam amount CY, C s splt nto C CY n "normal clam" amount CY, b and C "bg clam amount" analytcal nsurance rsk model CY, n CY, b PY modelng of ( C, C, C ) descrbes adequately realty except for extraordnary stuatons scenaros complements analytcal model to take nto account extraordnary stuatons; to take nto account extraordnary stuatons; by means of scenros SC k, k=1,,...,k, charactersed by face amounts c k wth occurrence probabltes p k. 4 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
5 Modelng n SST: Insurance Rsk Rsk measure n the SST 99% expected shortfall SCR for nsurance rsk [ ] SCR = ES TR ns 99%. 5 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
6 Modelng n SST: normal clam amount CY Model assumpton ( ) T Condtonal on Θ = Θ, Θ, CY, n C 1 s compound Posson; Θ1, Θ are random factors wth expected value 1 ndcatng how much next year's "true underlyng" clam frequency and the "true underlyng" expected clam severty wll devate from ther a pror expected values due to thngs lke weather condtons, change n economc envronment, change n legslaton, etc. Θ (, ) = Θ Θ T 1 s the "rsk characterstcs" of next year for lob ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators 6
7 Modelng n SST: normal clam amount CY CY, n C X =, where P varance structure from model assumptons follows that σ where P, param = E C CY, n σ fluct, : = Var( X ) = σ +, ν ( ) Var( ) σ Var Θ + Θ, param 1, υ ( Y ) ( ) σ, = CoVa + 1. fluct pure rsk premum; and where CoVa Y ν ( υ ) ( ) w λ () = = = the coeffcent of varaton of the clam severtes, a pror expected number of clams. 7 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
8 Modelng n SST: normal clam amount CY aggregaton over lob CY, n the varance of X = C / P s calculated by assumng a correlaton matrx T ( ) ( j) Corr( X X ) R = Corr X, X ( R, =, ) CY CY j => σ ( ) = 1 T := Var X ( W R W ) CY CY CY P, where ( P1σ1 Pσ Pσ ) W =,,,. CY I I T 8 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
9 Modelng n SST: bg clam amount CY Model Assumptons, ) for each lob the bg clam amount C CY b s compound Possondstrbuton wth (essentally) Pareto-dstrbuted clam szes ), C CY b, = 1,,, I are ndependent I CY, b CY, b => C s agan compound Posson wth = C = 1 λ I n b b b λ = λ = λ, F = b = 1 = 1 λ F. 9 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
10 Modelng n SST: normal and bg clam amount CY lob and standard parameters normal and bg clam amount CY 10 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
11 Modelng n SST: clam amount PY Reserve rsk (clam amount PY) L = outstandng clams labltes at 1.1. for lob, R = best estmate of L per 1.1. = best estmate reserve, PY 31.1., PY R = PA + R = best estmate of L per 31.1., R Y =. R note that C = R R PY Model Assumptons t s assumed that τ. τ : = Var( Y ) = τ + R, param fluct, 11 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
12 Modelng n SST: clam amount PY current standard parameters for PY-rsks 1 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
13 Modelng n SST: clam amount PY aggregaton over lob the varance of Y = R / R s calculated by assumng a correlaton matrx T ( Y ) ( j) Corr( Y Y ) R = Corr, Y ( R, =, ) PY PY j current standard SST assumpton Y, =1,,...,I, are ndependent,.e. R PY = dentty matrx. => τ 1 I : = Var( Y) = R τ R = 1 Dscusson on correlaton assumpton current standard SST assumpton s questonable; reason: calendar year effects affectng several lob smultaneously; an obvous example of s clams nflaton. 13 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
14 Modelng n SST: combned normal clam amount CY + clam amount PY Notatons CY, n + CY, n + = + C R PX RY S, = =, = C R Z V +, + P R P R P + R C + R P X + RY S C R, Z, V P R. CY, n CY, n = + = = = + P + R P + R Model assumpton It s assumed that s lognormal dstrbuted wth S [ ] = WCY WCY ES P + R, Var( S ) = R. WPY WPY T 14 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
15 Modelng n SST: combned normal clam amount CY + clam amount PY Correlaton matrces: R T X X RCY RCY, PY = Corr, =, Y Y RCY, PY RPY where R = Corr, CY, PY T ( X Y ) current standard SST assumpton current year clams and prevous year clams are uncorrelated, that s R = 0. CY, PY => Var ( Z ) = P σ + R ( P + R ) τ 15 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
16 Modelng n SST: correlaton CY and PY; convoluton wth bg clams Dscusson on correlaton assumpton between CY and PY current standard SST assumpton s questonable; reason: calendar year effects affectng the CY-year clam amount as the prevous years' clam amounts of several lob smultaneously; an example of such a calendar year effect s clams nflaton; Convoluton wth bg clam,, The dstrbuton of T = C CY n CY b PY can be calculated by + C + C convolutng the lognormal dstrbuton of CY, n PY C wth the + C CY, b compound Posson dstrbuton of => dstrbuton F before scenaros C 16 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
17 Modelng n SST: scenaros Model Assumptons: ns Scenaros SC k, k=1,,...,k, are characterzed by face amounts c k and occurrence probabltes p k. It s assumed that only one of the scenaros can occur wthn the next year (mutual excluson of scenaros). Remark: The "excluson assumpton" s not such a bg restrcton as t seems, snce one s free n defnng the scenaros. One can always defne new scenaros combnng two already exstng scenaros. Dstrbuton after scenaros,, dstrbuton functon of T = C CY n + C CY b + C PY + SC ns : K ( ) k ( k) 0 k 0 F x = p F x c, where p = 1 p and c = 0. k= 0 k= 1 K 17 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
18 Modelng n SII: Insurance rsk General to compare wth SST: only one regon, company s workng n; SCR for non-lfe nsurance rsk s named SCR nl n solvency II (SII). SII also consders CY-rsk (named premum rsk) and PY-rsk called reserve rsk. For CY-rsk : no dstncton s made between normal and bg clams. In addton: CAT-rsks, manly thought for natural perl rsks. Characterzed by face amounts smlar to the scenaro rsks n the SST. SII provdes formulas how to calculate the SCR and not models. Models presented here = models leadng to the formulas n SII to calculate the SCR. 18 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
19 Modelng n SII: Insurance rsk Notaton X CY C R = (loss rato CY), Y =, P R σ ( X ) τ Var( Y ) = Var, =, where P R R = = = premum reserve per 1.1. "a posteror reserves" per 31.1.of L. 19 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
20 Modelng n SII: premum (CY) rsk calculaton premum rsk per lob where ( ) σ = α σ + 1 α σ,, nd, M α σ σ = = credblty weght, standard "market" parameter, M, n n 1 P j P j nd, = Xj X X = Xj n 1 j= 1P j= 1P Model assumpton CY-rsk (premum rsk) Nether σ M, nor the credblty weght depend on the sze of the company => model assumpton: Var X = σ Model assumpton PY-rsk (reserve rsk) model assumpton: Var =. ( ) wth. ( ). ( ) τ y 0 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
21 Modelng n SII: premum + reserve rsk premum + reserve rsk per lob 1 Z = ( PX + RY ), where V = P + R. V ( X Y ) ρ, Assumpton: Corr, = = 50% ( Z ) => ϕ = Var = CY PY correlaton and aggregaton ( Pσ ) + ρ Pσ Rτ + ( Rτ ) CY, PY :. V ( Z Zj) = ρj ρj assumpton: Corr,, gven standard parameters V Z Z Z VV ϕ ϕ I I j j = => ϕ = Var( ) = ρ, j = 1 V, j= 1 V 1 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
22 Modelng n SII: premum + reserve rsk mplcatons and dscusson of correlaton assumptons Corr must hold for any company => ( Z Z ) ρ Corr( X Y ) ρ,, =,, = = 50%. j j CY PY ( ) ( ) ( ) Corr X, X = Corr Y, Y = Corr Z, Z = ρ, j j j j correlaton between lob result from calendar year effects affectng several lob smultaneously. To assume the same correlaton matrx for X and for Y s questonable, snce the calendar year effect for CY- and PY-rsks mght not be the same or mght have a dfferent mpact. Corr( X, Yj) for j depend on the volumes and dffcult to nterpret ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
23 Modelng n SII: formula to calculate SCR lob and parameters 3 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
24 Modelng n SII: premum + reserve rsk formula for SCR premum + reserve rsk SCR pr + res ( ( ) ϕ ) 1 Φ + exp log( 1) = V 1 ϕ + 1 VVaR ( ) mean = Ψ where Φ ( x) = standard normal dstrbuton. [ ] Var( ) ϕ Ψ= logormal dstrbuted r.v. wth E Ψ = 1 and Ψ =, ( ) ( Ψ ) = Ψ ( Ψ) VaR VaR E mean ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
25 Modelng n SII: premum + reserve rsk model assumpton behnd ths formula S E[ S ] has the same dstrbuton as V ( Ψ 1, ) where has a lognormal dstrbuton wth E Ψ = 1 and Var Ψ =. Ψ [ ] ( ) ϕ remarks and dscusson [ ] [ ] but contrary to the SST: ( ) ( ) S E S = V Z E Z s aproxmated by V Ψ 1. E[ Z ] 1 (usually smaller than 1). S [ ] => s modeled by a lognormal dstrbuton wth mean ES, but wth a varance whch s dfferent from Var [ S ] 5 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
26 Modelng n SII: premum + reserve rsk [ ] Comparson of 99.5% VaR of Z E Z and 1 for E Z = Ψ [ ] 85%. 6 DAV Scentfc Day , Berln / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
27 Modelng n SII: cat rsks and total nsurance rsk SCR for CAT rsks SCR CAT K = c k = 1 k. total SCR for nl-nsurance rsk SCR = SCR + SCR nl CY + PY CAT. model assumptons behnd these formulas The cat rsks CAT, = are ndependent and normally k k 1,,, I dstrbuted wth VaR CAT c ( ) = k k. Same assumpton for aggregatng the cat rsks and the other nsurance rsks. 7 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
28 Modelng : Summary STT and SII "parametrzed" models; SII: factor model; STT dstrbuton based model; rsk measure: STT 99% expected shortfall, SII 99.5% VaR varance assumptons CY- und PY-rsks (for r.v. X and Y): STT: parameter rsk and random fluctuaton rsk, where the latter s nversely proportonal to the weght (sze of the company); SII: CY- and PY-rsks not dependent on the sze of the company CY rsk: STT dstngushes between "normal clams" and "bg clams". No such dstncton n SII. Correlaton Assumptons (current state): SST: no correlatons between lob for the reserve rsks and no correlatons between CYund PY-rsks; SII: same correlaton between lob for CY- and PY-rsks; SST as well as SII assumptons not fully satsfactory. 8 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
29 Modelng : Summary SST: scenaros for extraordnary stuatons can be taken nto account n a natural way n the dstrbuton calculaton; SII: CAT-rsks modeled smlar to scenaros n the SST; however aggregaton of cat-rsks and wth CY/PY-rsks questonable SST: fnal product s a dstrbuton, from whch the SCR s calculated; SII: fnal product s one fgure, the SCR. Results (AXA-Wnterthur) wth current standard parameters: SCR ns hgher n SII than n SST; splt between CY- und PY-rsks: SII: ca 5% CY and 75% PY SST: ca 7% CY and 73% PY 9 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
30 Parameter Estmators: SII parameters straghtforward estmators σ n 1 P = X X j ˆ ( j ), n 1 j = 1 P n 1 R Y Y j ˆ = ( j ), n 1 j = 1 R τ Remarks: can overestmate the rsk n case of "strong" busness cycles n the observaton perod; often underestmates the reserve rsks because of "smoothng" effects n the reserves σˆ τˆ 30 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
31 Parameter Estmators: SST parameters Random fluctuaton rsk CY CoVa ( ( ν ) Y ) σ, = CoVa + 1. fluct j = 1 N 1 j Nj υ= 1 ( ( ν ) Y ) j Y Y n long-tal lob: above estmator underestmates the CoVa n recent accdent years 31 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
32 Parameter Estmators: SST parameters parameter rsk CY T specfc lob; each year j characterzed by Θ = Θ, Θ ; r.v. belongng to dfferent years are ndependent and Θ1, Θ,, 1 ΘJ are..d. => ( 1 ) j j j σ σ E X = 1, = + +, fluct ˆfluct j Var( X j ) σparam σparam ν j P j fulfll the assumptons of the Bü-Straub credblty model => estmator J w ( j ) J ˆ σ J j fluct ˆ param = c X X, J 1 j = 1 w n σ where 1 I I 1 w ( ( ) 1, ˆ ) w υ c = σ fluct = CoVa Y + 1, I = 1 w w n = observed number of clams. 3 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
33 Parameter Estmators: SST parameters parameter rsk CY (contnued) snce σ Var Θ + Var Θ param one can, alternatvely to the estmator gven before, estmate the two components separately based on the observed clam frequences and the observed clam szes. Here agan one can use a credblty procedure. more detals: see paper ( ) ( ) 1 33 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
34 Parameter Estmators: SST parameters Estmaton of the Pareto parameters for bg clam CY ML-estmator (adjusted for unbasedness) b n ˆ 1 Y ν ϑ = ln n 1ν = 1 c 1 wth E ( ˆ) ˆ 1 ϑ = ϑ, CoVa ϑ =. n Number of observed bg clams often rather small; combne ndvdual estmate wth market wde estmate; ML-estmators fulfll Bü-Straub cred. assumptons => credblty estmator ˆcred ϑ = αϑˆ + (1 α) ϑ0 where n, standard value from the SST, ϑ ( ). 0 = κ = CoVa Θ n 1+ κ ( ) 5%, n=16 Example: CoVa Θ = => gve a credblty weght of 3% to your ndvdual estmate 34 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
35 Parameter Estmators: SST parameters reserve rsk reserve rsk should be valuated wth reservng technques; well known: Mack's mse of the ultmate for chan ladder reservng method; for solvency purposes one needs the one-year reserve rsk; the formula can be found n Bühlmann and alas (009); In Solvency we are nterested n the one n a century adverse reserve events. What scenaros come to our mnd: for nstance a hyper-nflaton or a bg change n legslaton. These are "calendar-year" events not observed n the trangles and not captured by standard reservng methods. => the reserve rsk resultng from standard reservng methods are not suffcent for solvency purposes and should be supplemented by reserve scenaros. 35 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
36 Parameter Estmators: SST parameters reserve rsk (contnued) For small and medum szed companes the observed fgures n a development trangle mght fluctuate a lot. It would be helpful f one could combne ndustry wde patterns wth the one evaluated wth the data of the ndvdual company. For chan ladder a credblty method was developed of how one could combne the nformaton ganed from the two sources: ndvdual data and ndustry wde nformaton. The dea s to estmate the age-to-age factors by credblty technques. For more nformaton see Gsler-Wüthrch (008). 36 ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
37 References Bühlmann, H., De Felce M., Gsler, A., Morcon F., Wüthrch, M.V. (009). Recursve Credblty Formula for Chan Ladder Factors and the Clam Development Result. Forthcomng n the ASTIN Bulletn. Gsler, A., Wüthrch, M.V. (008).Credblty for the Chan Ladder Reservng Method. ASTIN Bulletn 38/, Gsler, A. (009). The Insurance Rsk n the SST and n Solvency II: Modellng and Parameter Estmaton. ASTIN Colloquum n Helsnk. Merz, M., Wüthrch M.V. (008). Modellng the clams development result for solvency purposes. CAS Forum, Fall 008, ASTIN Colloquum, 1-4 June 009, Helsnk / A. Gsler / The Insurance Rsk n the SST and n Solvency II: Modelng and Parameter Estmators
Development Pattern and Prediction Error for the Stochastic Bornhuetter-Ferguson Claims Reserving Method
Development Pattern and Predcton Error for the Stochastc Bornhuetter-Ferguson Clams Reservng Method Annna Saluz, Alos Gsler, Maro V. Wüthrch ETH Zurch ASTIN Colloquum Madrd, June 2011 Overvew 1 Notaton
More informationPreface to members of the Risk Theory Society
Preface to members of the Rsk Theory Socety Below s an excerpt of my proposal for ths meetng. To summarze: 1. The paper I submtted s ttled The Common Shock Model for Correlated Insurance Losses.. The ttle
More informationJAB Chain. Long-tail claims development. ASTIN - September 2005 B.Verdier A. Klinger
JAB Chan Long-tal clams development ASTIN - September 2005 B.Verder A. Klnger Outlne Chan Ladder : comments A frst soluton: Munch Chan Ladder JAB Chan Chan Ladder: Comments Black lne: average pad to ncurred
More information1. Inference on Regression Parameters a. Finding Mean, s.d and covariance amongst estimates. 2. Confidence Intervals and Working Hotelling Bands
Content. Inference on Regresson Parameters a. Fndng Mean, s.d and covarance amongst estmates.. Confdence Intervals and Workng Hotellng Bands 3. Cochran s Theorem 4. General Lnear Testng 5. Measures of
More informationLINEAR REGRESSION ANALYSIS. MODULE IX Lecture Multicollinearity
LINEAR REGRESSION ANALYSIS MODULE IX Lecture - 30 Multcollnearty Dr. Shalabh Department of Mathematcs and Statstcs Indan Insttute of Technology Kanpur 2 Remedes for multcollnearty Varous technques have
More informationTopic 23 - Randomized Complete Block Designs (RCBD)
Topc 3 ANOVA (III) 3-1 Topc 3 - Randomzed Complete Block Desgns (RCBD) Defn: A Randomzed Complete Block Desgn s a varant of the completely randomzed desgn (CRD) that we recently learned. In ths desgn,
More informationComputation of Higher Order Moments from Two Multinomial Overdispersion Likelihood Models
Computaton of Hgher Order Moments from Two Multnomal Overdsperson Lkelhood Models BY J. T. NEWCOMER, N. K. NEERCHAL Department of Mathematcs and Statstcs, Unversty of Maryland, Baltmore County, Baltmore,
More informationLimited Dependent Variables
Lmted Dependent Varables. What f the left-hand sde varable s not a contnuous thng spread from mnus nfnty to plus nfnty? That s, gven a model = f (, β, ε, where a. s bounded below at zero, such as wages
More informationj) = 1 (note sigma notation) ii. Continuous random variable (e.g. Normal distribution) 1. density function: f ( x) 0 and f ( x) dx = 1
Random varables Measure of central tendences and varablty (means and varances) Jont densty functons and ndependence Measures of assocaton (covarance and correlaton) Interestng result Condtonal dstrbutons
More informationChapter 13: Multiple Regression
Chapter 13: Multple Regresson 13.1 Developng the multple-regresson Model The general model can be descrbed as: It smplfes for two ndependent varables: The sample ft parameter b 0, b 1, and b are used to
More informationStatistics for Business and Economics
Statstcs for Busness and Economcs Chapter 11 Smple Regresson Copyrght 010 Pearson Educaton, Inc. Publshng as Prentce Hall Ch. 11-1 11.1 Overvew of Lnear Models n An equaton can be ft to show the best lnear
More informationEcon107 Applied Econometrics Topic 3: Classical Model (Studenmund, Chapter 4)
I. Classcal Assumptons Econ7 Appled Econometrcs Topc 3: Classcal Model (Studenmund, Chapter 4) We have defned OLS and studed some algebrac propertes of OLS. In ths topc we wll study statstcal propertes
More informationDepartment of Quantitative Methods & Information Systems. Time Series and Their Components QMIS 320. Chapter 6
Department of Quanttatve Methods & Informaton Systems Tme Seres and Ther Components QMIS 30 Chapter 6 Fall 00 Dr. Mohammad Zanal These sldes were modfed from ther orgnal source for educatonal purpose only.
More informationx i1 =1 for all i (the constant ).
Chapter 5 The Multple Regresson Model Consder an economc model where the dependent varable s a functon of K explanatory varables. The economc model has the form: y = f ( x,x,..., ) xk Approxmate ths by
More informationMaximum Likelihood Estimation of Binary Dependent Variables Models: Probit and Logit. 1. General Formulation of Binary Dependent Variables Models
ECO 452 -- OE 4: Probt and Logt Models ECO 452 -- OE 4 Maxmum Lkelhood Estmaton of Bnary Dependent Varables Models: Probt and Logt hs note demonstrates how to formulate bnary dependent varables models
More informationDr. Shalabh Department of Mathematics and Statistics Indian Institute of Technology Kanpur
Analyss of Varance and Desgn of Exerments-I MODULE III LECTURE - 2 EXPERIMENTAL DESIGN MODELS Dr. Shalabh Deartment of Mathematcs and Statstcs Indan Insttute of Technology Kanur 2 We consder the models
More information4 Analysis of Variance (ANOVA) 5 ANOVA. 5.1 Introduction. 5.2 Fixed Effects ANOVA
4 Analyss of Varance (ANOVA) 5 ANOVA 51 Introducton ANOVA ANOVA s a way to estmate and test the means of multple populatons We wll start wth one-way ANOVA If the populatons ncluded n the study are selected
More informationLow default modelling: a comparison of techniques based on a real Brazilian corporate portfolio
Low default modellng: a comparson of technques based on a real Brazlan corporate portfolo MSc Gulherme Fernandes and MSc Carlos Rocha Credt Scorng and Credt Control Conference XII August 2011 Analytcs
More information/ n ) are compared. The logic is: if the two
STAT C141, Sprng 2005 Lecture 13 Two sample tests One sample tests: examples of goodness of ft tests, where we are testng whether our data supports predctons. Two sample tests: called as tests of ndependence
More informationComparison of the Population Variance Estimators. of 2-Parameter Exponential Distribution Based on. Multiple Criteria Decision Making Method
Appled Mathematcal Scences, Vol. 7, 0, no. 47, 07-0 HIARI Ltd, www.m-hkar.com Comparson of the Populaton Varance Estmators of -Parameter Exponental Dstrbuton Based on Multple Crtera Decson Makng Method
More informationDr. Shalabh Department of Mathematics and Statistics Indian Institute of Technology Kanpur
Analyss of Varance and Desgn of Experment-I MODULE VII LECTURE - 3 ANALYSIS OF COVARIANCE Dr Shalabh Department of Mathematcs and Statstcs Indan Insttute of Technology Kanpur Any scentfc experment s performed
More informationSTAT 511 FINAL EXAM NAME Spring 2001
STAT 5 FINAL EXAM NAME Sprng Instructons: Ths s a closed book exam. No notes or books are allowed. ou may use a calculator but you are not allowed to store notes or formulas n the calculator. Please wrte
More informationPredictive Analytics : QM901.1x Prof U Dinesh Kumar, IIMB. All Rights Reserved, Indian Institute of Management Bangalore
Sesson Outlne Introducton to classfcaton problems and dscrete choce models. Introducton to Logstcs Regresson. Logstc functon and Logt functon. Maxmum Lkelhood Estmator (MLE) for estmaton of LR parameters.
More informationCredit Card Pricing and Impact of Adverse Selection
Credt Card Prcng and Impact of Adverse Selecton Bo Huang and Lyn C. Thomas Unversty of Southampton Contents Background Aucton model of credt card solctaton - Errors n probablty of beng Good - Errors n
More informationSampling Theory MODULE V LECTURE - 17 RATIO AND PRODUCT METHODS OF ESTIMATION
Samplng Theory MODULE V LECTURE - 7 RATIO AND PRODUCT METHODS OF ESTIMATION DR. SHALABH DEPARTMENT OF MATHEMATICS AND STATISTICS INDIAN INSTITUTE OF TECHNOLOG KANPUR Propertes of separate rato estmator:
More informationThe Multiple Classical Linear Regression Model (CLRM): Specification and Assumptions. 1. Introduction
ECONOMICS 5* -- NOTE (Summary) ECON 5* -- NOTE The Multple Classcal Lnear Regresson Model (CLRM): Specfcaton and Assumptons. Introducton CLRM stands for the Classcal Lnear Regresson Model. The CLRM s also
More informationStochastic Claims Reserving under Consideration of Various Different Sources of Information
Stochastc Clams Reservng under Consderaton of Varous Dfferent Sources of Informaton Dssertaton Zur Erlangung der Würde des Dotors der Wrtschaftswssenschaften der Unverstät Hamburg vorgelegt von Sebastan
More informationBasically, if you have a dummy dependent variable you will be estimating a probability.
ECON 497: Lecture Notes 13 Page 1 of 1 Metropoltan State Unversty ECON 497: Research and Forecastng Lecture Notes 13 Dummy Dependent Varable Technques Studenmund Chapter 13 Bascally, f you have a dummy
More informationANSWERS. Problem 1. and the moment generating function (mgf) by. defined for any real t. Use this to show that E( U) var( U)
Econ 413 Exam 13 H ANSWERS Settet er nndelt 9 deloppgaver, A,B,C, som alle anbefales å telle lkt for å gøre det ltt lettere å stå. Svar er gtt . Unfortunately, there s a prntng error n the hnt of
More informationEcon107 Applied Econometrics Topic 9: Heteroskedasticity (Studenmund, Chapter 10)
I. Defnton and Problems Econ7 Appled Econometrcs Topc 9: Heteroskedastcty (Studenmund, Chapter ) We now relax another classcal assumpton. Ths s a problem that arses often wth cross sectons of ndvduals,
More informationChapter 2 - The Simple Linear Regression Model S =0. e i is a random error. S β2 β. This is a minimization problem. Solution is a calculus exercise.
Chapter - The Smple Lnear Regresson Model The lnear regresson equaton s: where y + = β + β e for =,..., y and are observable varables e s a random error How can an estmaton rule be constructed for the
More informationChapter 14 Simple Linear Regression
Chapter 4 Smple Lnear Regresson Chapter 4 - Smple Lnear Regresson Manageral decsons often are based on the relatonshp between two or more varables. Regresson analss can be used to develop an equaton showng
More informatione i is a random error
Chapter - The Smple Lnear Regresson Model The lnear regresson equaton s: where + β + β e for,..., and are observable varables e s a random error How can an estmaton rule be constructed for the unknown
More informationStructure and Drive Paul A. Jensen Copyright July 20, 2003
Structure and Drve Paul A. Jensen Copyrght July 20, 2003 A system s made up of several operatons wth flow passng between them. The structure of the system descrbes the flow paths from nputs to outputs.
More informationsince [1-( 0+ 1x1i+ 2x2 i)] [ 0+ 1x1i+ assumed to be a reasonable approximation
Econ 388 R. Butler 204 revsons Lecture 4 Dummy Dependent Varables I. Lnear Probablty Model: the Regresson model wth a dummy varables as the dependent varable assumpton, mplcaton regular multple regresson
More informationTHE ROYAL STATISTICAL SOCIETY 2006 EXAMINATIONS SOLUTIONS HIGHER CERTIFICATE
THE ROYAL STATISTICAL SOCIETY 6 EXAMINATIONS SOLUTIONS HIGHER CERTIFICATE PAPER I STATISTICAL THEORY The Socety provdes these solutons to assst canddates preparng for the eamnatons n future years and for
More informationMaximum Likelihood Estimation of Binary Dependent Variables Models: Probit and Logit. 1. General Formulation of Binary Dependent Variables Models
ECO 452 -- OE 4: Probt and Logt Models ECO 452 -- OE 4 Mamum Lkelhood Estmaton of Bnary Dependent Varables Models: Probt and Logt hs note demonstrates how to formulate bnary dependent varables models for
More informationChapter 11: Simple Linear Regression and Correlation
Chapter 11: Smple Lnear Regresson and Correlaton 11-1 Emprcal Models 11-2 Smple Lnear Regresson 11-3 Propertes of the Least Squares Estmators 11-4 Hypothess Test n Smple Lnear Regresson 11-4.1 Use of t-tests
More informationPrimer on High-Order Moment Estimators
Prmer on Hgh-Order Moment Estmators Ton M. Whted July 2007 The Errors-n-Varables Model We wll start wth the classcal EIV for one msmeasured regressor. The general case s n Erckson and Whted Econometrc
More informationChapter 8 Indicator Variables
Chapter 8 Indcator Varables In general, e explanatory varables n any regresson analyss are assumed to be quanttatve n nature. For example, e varables lke temperature, dstance, age etc. are quanttatve n
More informationStat 642, Lecture notes for 01/27/ d i = 1 t. n i t nj. n j
Stat 642, Lecture notes for 01/27/05 18 Rate Standardzaton Contnued: Note that f T n t where T s the cumulatve follow-up tme and n s the number of subjects at rsk at the mdpont or nterval, and d s the
More informationOnline Appendix. t=1 (p t w)q t. Then the first order condition shows that
Artcle forthcomng to ; manuscrpt no (Please, provde the manuscrpt number!) 1 Onlne Appendx Appendx E: Proofs Proof of Proposton 1 Frst we derve the equlbrum when the manufacturer does not vertcally ntegrate
More informationRandom Partitions of Samples
Random Parttons of Samples Klaus Th. Hess Insttut für Mathematsche Stochastk Technsche Unverstät Dresden Abstract In the present paper we construct a decomposton of a sample nto a fnte number of subsamples
More informationChapter 7 Generalized and Weighted Least Squares Estimation. In this method, the deviation between the observed and expected values of
Chapter 7 Generalzed and Weghted Least Squares Estmaton The usual lnear regresson model assumes that all the random error components are dentcally and ndependently dstrbuted wth constant varance. When
More informationParametric fractional imputation for missing data analysis. Jae Kwang Kim Survey Working Group Seminar March 29, 2010
Parametrc fractonal mputaton for mssng data analyss Jae Kwang Km Survey Workng Group Semnar March 29, 2010 1 Outlne Introducton Proposed method Fractonal mputaton Approxmaton Varance estmaton Multple mputaton
More informationLINEAR REGRESSION ANALYSIS. MODULE VIII Lecture Indicator Variables
LINEAR REGRESSION ANALYSIS MODULE VIII Lecture - 7 Indcator Varables Dr. Shalabh Department of Maematcs and Statstcs Indan Insttute of Technology Kanpur Indcator varables versus quanttatve explanatory
More informationLinear Approximation with Regularization and Moving Least Squares
Lnear Approxmaton wth Regularzaton and Movng Least Squares Igor Grešovn May 007 Revson 4.6 (Revson : March 004). 5 4 3 0.5 3 3.5 4 Contents: Lnear Fttng...4. Weghted Least Squares n Functon Approxmaton...
More informationELASTIC WAVE PROPAGATION IN A CONTINUOUS MEDIUM
ELASTIC WAVE PROPAGATION IN A CONTINUOUS MEDIUM An elastc wave s a deformaton of the body that travels throughout the body n all drectons. We can examne the deformaton over a perod of tme by fxng our look
More informationAndreas C. Drichoutis Agriculural University of Athens. Abstract
Heteroskedastcty, the sngle crossng property and ordered response models Andreas C. Drchouts Agrculural Unversty of Athens Panagots Lazards Agrculural Unversty of Athens Rodolfo M. Nayga, Jr. Texas AMUnversty
More informationResource Allocation and Decision Analysis (ECON 8010) Spring 2014 Foundations of Regression Analysis
Resource Allocaton and Decson Analss (ECON 800) Sprng 04 Foundatons of Regresson Analss Readng: Regresson Analss (ECON 800 Coursepak, Page 3) Defntons and Concepts: Regresson Analss statstcal technques
More informationStatistics for Economics & Business
Statstcs for Economcs & Busness Smple Lnear Regresson Learnng Objectves In ths chapter, you learn: How to use regresson analyss to predct the value of a dependent varable based on an ndependent varable
More informationISQS 6348 Final Open notes, no books. Points out of 100 in parentheses. Y 1 ε 2
ISQS 6348 Fnal Open notes, no books. Ponts out of 100 n parentheses. 1. The followng path dagram s gven: ε 1 Y 1 ε F Y 1.A. (10) Wrte down the usual model and assumptons that are mpled by ths dagram. Soluton:
More informationRockefeller College University at Albany
Rockefeller College Unverst at Alban PAD 705 Handout: Maxmum Lkelhood Estmaton Orgnal b Davd A. Wse John F. Kenned School of Government, Harvard Unverst Modfcatons b R. Karl Rethemeer Up to ths pont n
More informationx = , so that calculated
Stat 4, secton Sngle Factor ANOVA notes by Tm Plachowsk n chapter 8 we conducted hypothess tests n whch we compared a sngle sample s mean or proporton to some hypotheszed value Chapter 9 expanded ths to
More information2E Pattern Recognition Solutions to Introduction to Pattern Recognition, Chapter 2: Bayesian pattern classification
E395 - Pattern Recognton Solutons to Introducton to Pattern Recognton, Chapter : Bayesan pattern classfcaton Preface Ths document s a soluton manual for selected exercses from Introducton to Pattern Recognton
More informationRELIABILITY ASSESSMENT
CHAPTER Rsk Analyss n Engneerng and Economcs RELIABILITY ASSESSMENT A. J. Clark School of Engneerng Department of Cvl and Envronmental Engneerng 4a CHAPMAN HALL/CRC Rsk Analyss for Engneerng Department
More informationA Robust Method for Calculating the Correlation Coefficient
A Robust Method for Calculatng the Correlaton Coeffcent E.B. Nven and C. V. Deutsch Relatonshps between prmary and secondary data are frequently quantfed usng the correlaton coeffcent; however, the tradtonal
More informationFirst Year Examination Department of Statistics, University of Florida
Frst Year Examnaton Department of Statstcs, Unversty of Florda May 7, 010, 8:00 am - 1:00 noon Instructons: 1. You have four hours to answer questons n ths examnaton.. You must show your work to receve
More informationComposite Hypotheses testing
Composte ypotheses testng In many hypothess testng problems there are many possble dstrbutons that can occur under each of the hypotheses. The output of the source s a set of parameters (ponts n a parameter
More informationConvergence of random processes
DS-GA 12 Lecture notes 6 Fall 216 Convergence of random processes 1 Introducton In these notes we study convergence of dscrete random processes. Ths allows to characterze phenomena such as the law of large
More informationEconomics 130. Lecture 4 Simple Linear Regression Continued
Economcs 130 Lecture 4 Contnued Readngs for Week 4 Text, Chapter and 3. We contnue wth addressng our second ssue + add n how we evaluate these relatonshps: Where do we get data to do ths analyss? How do
More informationβ0 + β1xi and want to estimate the unknown
SLR Models Estmaton Those OLS Estmates Estmators (e ante) v. estmates (e post) The Smple Lnear Regresson (SLR) Condtons -4 An Asde: The Populaton Regresson Functon B and B are Lnear Estmators (condtonal
More informationBayesian predictive Configural Frequency Analysis
Psychologcal Test and Assessment Modelng, Volume 54, 2012 (3), 285-292 Bayesan predctve Confgural Frequency Analyss Eduardo Gutérrez-Peña 1 Abstract Confgural Frequency Analyss s a method for cell-wse
More informationRecall that quantitative genetics is based on the extension of Mendelian principles to polygenic traits.
BIOSTT/STT551, Statstcal enetcs II: Quanttatve Trats Wnter 004 Sources of varaton for multlocus trats and Handout Readng: Chapter 5 and 6. Extensons to Multlocus trats Recall that quanttatve genetcs s
More informationThe Order Relation and Trace Inequalities for. Hermitian Operators
Internatonal Mathematcal Forum, Vol 3, 08, no, 507-57 HIKARI Ltd, wwwm-hkarcom https://doorg/0988/mf088055 The Order Relaton and Trace Inequaltes for Hermtan Operators Y Huang School of Informaton Scence
More informationNegative Binomial Regression
STATGRAPHICS Rev. 9/16/2013 Negatve Bnomal Regresson Summary... 1 Data Input... 3 Statstcal Model... 3 Analyss Summary... 4 Analyss Optons... 7 Plot of Ftted Model... 8 Observed Versus Predcted... 10 Predctons...
More informationSee Book Chapter 11 2 nd Edition (Chapter 10 1 st Edition)
Count Data Models See Book Chapter 11 2 nd Edton (Chapter 10 1 st Edton) Count data consst of non-negatve nteger values Examples: number of drver route changes per week, the number of trp departure changes
More informationUncertainty as the Overlap of Alternate Conditional Distributions
Uncertanty as the Overlap of Alternate Condtonal Dstrbutons Olena Babak and Clayton V. Deutsch Centre for Computatonal Geostatstcs Department of Cvl & Envronmental Engneerng Unversty of Alberta An mportant
More informationSIMPLE LINEAR REGRESSION
Smple Lnear Regresson and Correlaton Introducton Prevousl, our attenton has been focused on one varable whch we desgnated b x. Frequentl, t s desrable to learn somethng about the relatonshp between two
More informationHomework Assignment 3 Due in class, Thursday October 15
Homework Assgnment 3 Due n class, Thursday October 15 SDS 383C Statstcal Modelng I 1 Rdge regresson and Lasso 1. Get the Prostrate cancer data from http://statweb.stanford.edu/~tbs/elemstatlearn/ datasets/prostate.data.
More informationA Bayes Algorithm for the Multitask Pattern Recognition Problem Direct Approach
A Bayes Algorthm for the Multtask Pattern Recognton Problem Drect Approach Edward Puchala Wroclaw Unversty of Technology, Char of Systems and Computer etworks, Wybrzeze Wyspanskego 7, 50-370 Wroclaw, Poland
More informationThe optimal delay of the second test is therefore approximately 210 hours earlier than =2.
THE IEC 61508 FORMULAS 223 The optmal delay of the second test s therefore approxmately 210 hours earler than =2. 8.4 The IEC 61508 Formulas IEC 61508-6 provdes approxmaton formulas for the PF for smple
More informationProf. Dr. I. Nasser Phys 630, T Aug-15 One_dimensional_Ising_Model
EXACT OE-DIMESIOAL ISIG MODEL The one-dmensonal Isng model conssts of a chan of spns, each spn nteractng only wth ts two nearest neghbors. The smple Isng problem n one dmenson can be solved drectly n several
More informationUncertainty and auto-correlation in. Measurement
Uncertanty and auto-correlaton n arxv:1707.03276v2 [physcs.data-an] 30 Dec 2017 Measurement Markus Schebl Federal Offce of Metrology and Surveyng (BEV), 1160 Venna, Austra E-mal: markus.schebl@bev.gv.at
More informationLecture 4 Hypothesis Testing
Lecture 4 Hypothess Testng We may wsh to test pror hypotheses about the coeffcents we estmate. We can use the estmates to test whether the data rejects our hypothess. An example mght be that we wsh to
More informationIssues To Consider when Estimating Health Care Costs with Generalized Linear Models (GLMs): To Gamma/Log Or Not To Gamma/Log? That Is The New Question
Issues To Consder when Estmatng Health Care Costs wth Generalzed Lnear Models (GLMs): To Gamma/Log Or Not To Gamma/Log? That Is The New Queston ISPOR 20th Annual Internatonal Meetng May 19, 2015 Jalpa
More informationLecture 12: Classification
Lecture : Classfcaton g Dscrmnant functons g The optmal Bayes classfer g Quadratc classfers g Eucldean and Mahalanobs metrcs g K Nearest Neghbor Classfers Intellgent Sensor Systems Rcardo Guterrez-Osuna
More informationLINEAR REGRESSION ANALYSIS. MODULE IX Lecture Multicollinearity
LINEAR REGRESSION ANALYSIS MODULE IX Lecture - 31 Multcollnearty Dr. Shalabh Department of Mathematcs and Statstcs Indan Insttute of Technology Kanpur 6. Rdge regresson The OLSE s the best lnear unbased
More informationDiscussion of Extensions of the Gauss-Markov Theorem to the Case of Stochastic Regression Coefficients Ed Stanek
Dscusson of Extensons of the Gauss-arkov Theorem to the Case of Stochastc Regresson Coeffcents Ed Stanek Introducton Pfeffermann (984 dscusses extensons to the Gauss-arkov Theorem n settngs where regresson
More informationPROBABILITY PRIMER. Exercise Solutions
PROBABILITY PRIMER Exercse Solutons 1 Probablty Prmer, Exercse Solutons, Prncples of Econometrcs, e EXERCISE P.1 (b) X s a random varable because attendance s not known pror to the outdoor concert. Before
More informationGMM Method (Single-equation) Pongsa Pornchaiwiseskul Faculty of Economics Chulalongkorn University
GMM Method (Sngle-equaton Pongsa Pornchawsesul Faculty of Economcs Chulalongorn Unversty Stochastc ( Gven that, for some, s random COV(, ε E(( µ ε E( ε µ E( ε E( ε (c Pongsa Pornchawsesul, Faculty of Economcs,
More information18.1 Introduction and Recap
CS787: Advanced Algorthms Scrbe: Pryananda Shenoy and Shjn Kong Lecturer: Shuch Chawla Topc: Streamng Algorthmscontnued) Date: 0/26/2007 We contnue talng about streamng algorthms n ths lecture, ncludng
More informationStatistics II Final Exam 26/6/18
Statstcs II Fnal Exam 26/6/18 Academc Year 2017/18 Solutons Exam duraton: 2 h 30 mn 1. (3 ponts) A town hall s conductng a study to determne the amount of leftover food produced by the restaurants n the
More informationAS-Level Maths: Statistics 1 for Edexcel
1 of 6 AS-Level Maths: Statstcs 1 for Edecel S1. Calculatng means and standard devatons Ths con ndcates the slde contans actvtes created n Flash. These actvtes are not edtable. For more detaled nstructons,
More informationGaussian Mixture Models
Lab Gaussan Mxture Models Lab Objectve: Understand the formulaton of Gaussan Mxture Models (GMMs) and how to estmate GMM parameters. You ve already seen GMMs as the observaton dstrbuton n certan contnuous
More informationA LINEAR PROGRAM TO COMPARE MULTIPLE GROSS CREDIT LOSS FORECASTS. Dr. Derald E. Wentzien, Wesley College, (302) ,
A LINEAR PROGRAM TO COMPARE MULTIPLE GROSS CREDIT LOSS FORECASTS Dr. Derald E. Wentzen, Wesley College, (302) 736-2574, wentzde@wesley.edu ABSTRACT A lnear programmng model s developed and used to compare
More informationHidden Markov Models
Hdden Markov Models Namrata Vaswan, Iowa State Unversty Aprl 24, 204 Hdden Markov Model Defntons and Examples Defntons:. A hdden Markov model (HMM) refers to a set of hdden states X 0, X,..., X t,...,
More informationSTAT 3014/3914. Semester 2 Applied Statistics Solution to Tutorial 13
STAT 304/394 Semester Appled Statstcs 05 Soluton to Tutoral 3. Note that s the total mleage for branch. a) -stage cluster sample Cluster branches N ; n 4) Element cars M 80; m 40) Populaton mean no. of
More informationUNIVERSITY OF TORONTO Faculty of Arts and Science. December 2005 Examinations STA437H1F/STA1005HF. Duration - 3 hours
UNIVERSITY OF TORONTO Faculty of Arts and Scence December 005 Examnatons STA47HF/STA005HF Duraton - hours AIDS ALLOWED: (to be suppled by the student) Non-programmable calculator One handwrtten 8.5'' x
More informationHowever, since P is a symmetric idempotent matrix, of P are either 0 or 1 [Eigen-values
Fall 007 Soluton to Mdterm Examnaton STAT 7 Dr. Goel. [0 ponts] For the general lnear model = X + ε, wth uncorrelated errors havng mean zero and varance σ, suppose that the desgn matrx X s not necessarly
More informationTransfer Functions. Convenient representation of a linear, dynamic model. A transfer function (TF) relates one input and one output: ( ) system
Transfer Functons Convenent representaton of a lnear, dynamc model. A transfer functon (TF) relates one nput and one output: x t X s y t system Y s The followng termnology s used: x y nput output forcng
More informationExplaining the Stein Paradox
Explanng the Sten Paradox Kwong Hu Yung 1999/06/10 Abstract Ths report offers several ratonale for the Sten paradox. Sectons 1 and defnes the multvarate normal mean estmaton problem and ntroduces Sten
More informationLinear Regression Analysis: Terminology and Notation
ECON 35* -- Secton : Basc Concepts of Regresson Analyss (Page ) Lnear Regresson Analyss: Termnology and Notaton Consder the generc verson of the smple (two-varable) lnear regresson model. It s represented
More informationLECTURE 9 CANONICAL CORRELATION ANALYSIS
LECURE 9 CANONICAL CORRELAION ANALYSIS Introducton he concept of canoncal correlaton arses when we want to quantfy the assocatons between two sets of varables. For example, suppose that the frst set of
More informationCS-433: Simulation and Modeling Modeling and Probability Review
CS-433: Smulaton and Modelng Modelng and Probablty Revew Exercse 1. (Probablty of Smple Events) Exercse 1.1 The owner of a camera shop receves a shpment of fve cameras from a camera manufacturer. Unknown
More informationChapter 3 Describing Data Using Numerical Measures
Chapter 3 Student Lecture Notes 3-1 Chapter 3 Descrbng Data Usng Numercal Measures Fall 2006 Fundamentals of Busness Statstcs 1 Chapter Goals To establsh the usefulness of summary measures of data. The
More informationProperties of Least Squares
Week 3 3.1 Smple Lnear Regresson Model 3. Propertes of Least Squares Estmators Y Y β 1 + β X + u weekly famly expendtures X weekly famly ncome For a gven level of x, the expected level of food expendtures
More informationWeek3, Chapter 4. Position and Displacement. Motion in Two Dimensions. Instantaneous Velocity. Average Velocity
Week3, Chapter 4 Moton n Two Dmensons Lecture Quz A partcle confned to moton along the x axs moves wth constant acceleraton from x =.0 m to x = 8.0 m durng a 1-s tme nterval. The velocty of the partcle
More informationChecking Pairwise Relationships. Lecture 19 Biostatistics 666
Checkng Parwse Relatonshps Lecture 19 Bostatstcs 666 Last Lecture: Markov Model for Multpont Analyss X X X 1 3 X M P X 1 I P X I P X 3 I P X M I 1 3 M I 1 I I 3 I M P I I P I 3 I P... 1 IBD states along
More informationSpatial Statistics and Analysis Methods (for GEOG 104 class).
Spatal Statstcs and Analyss Methods (for GEOG 104 class). Provded by Dr. An L, San Dego State Unversty. 1 Ponts Types of spatal data Pont pattern analyss (PPA; such as nearest neghbor dstance, quadrat
More information