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Accident
Analysis
and
Prevention
jo u r n al hom e p a g e :w w w . e l s e v i e r . c o m / l o c a t e / a a p
Modeling
crash
frequency
and
severity
using
multinomial-generalized
Poisson
model
with
error
components
Yu-Chiun
Chiou
∗,
Chiang
Fu
InstituteofTrafficandTransportation,NationalChiaoTungUniversity,4F,118,Sec.1,Chung-HsiaoW.Rd.,Taipei100,Taiwan
a
r
t
i
c
l
e
i
n
f
o
Articlehistory:Received16October2011
Receivedinrevisedform25March2012 Accepted26March2012 Keywords: Crashfrequency Crashseverity Multinomial-generalizedPoisson Errorcomponents
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Sincethefactorscontributingtocrashfrequencyandseverityusuallydiffer,anintegratedmodelunder themultinomialgeneralizedPoisson(MGP)architectureisproposedtoanalyzesimultaneouslycrash frequencyandseverity—makingestimationresultsincreasinglyefficientanduseful.Consideringthe substitutionpatternamongseveritylevelsandthesharederrorstructure,fourmodelsareproposed andcompared—theMGPmodelwithorwithouterrorcomponents(EMGPandMGPmodels, respec-tively)andtwonestedgeneralizedPoissonmodels(NGPmodel).Acasestudybasedonaccidentdatafor Taiwan’sNo.1Freewayisconducted.TheresultsshowthattheEMGPmodelhasthebestgoodness-of-fit andpredictionaccuracyindices.Additionally,estimationresultsshowthatfactorscontributingtocrash frequencyandseveritydiffermarkedly.Safetyimprovementstrategiesareproposedaccordingly.
© 2012 Elsevier Ltd. All rights reserved.
1. Introduction
Toimprovetrafficsafety,numerousstatisticalmodelshavebeen developed that identifyfactors contributing tocrash frequency andseverity.Mostidentifyriskfactorsforeithercrashfrequency orseverityindependently.Whenmodelingcrashfrequency(the numberofaccidentsonroadwaysegmentsoratintersectionsover aspecifiedperiod),aconsiderablenumberofstudieshaveused variousmethodologicalapproaches.Duetothediscreteand non-negativeintegercharacterofaccidentcounts,count-datamodels suchasthePoissonmodel(e.g.,Jonesetal.,1991;Miaou,1994; Shankaret al.,1997), negativebinomialmodel(e.g.,Hadietal., 1995; Shankar et al.,1995; Poch and Mannering,1996; Milton and Mannering, 1998; Lord, 2006; Malyshkina and Mannering, 2010),Poissonlognormalmodel(e.g.,Miaouetal.,2005;Lordand Miranda-Moreno,2008),Gammamodel(e.g.,Ohetal.,2006), gen-eralizedPoissonmodel(e.g.,Dissanayakeetal.,2009;Famoyeetal., 2004)aswellaszero-inflatedmodelingandotherflexiblemodeling techniques(e.g.,Abdel-AtyandRadwan,2000;Wangand Abdel-Aty,2008;ParkandLord,2009;AnastasopoulosandMannering, 2009;seeLordandMannering,2010forelaborateandcomplete reviews)havebeenappliedtomodelcrashcounts.
Crash frequencies are commonly collected by severity on relativelyhomogenousroadwaysegments,supportingthe devel-opment of crash count models. Thus, crash data are typically classified according to severity (e.g., property damage only, injury, and fatality) or collision type (e.g., rear-end, head-on,
∗ Correspondingauthor.Tel.:+886223494940;fax:+886223494953. E-mailaddress:ycchiou@mail.nctu.edu.tw(Y.-C.Chiou).
sideswipe,and rightangle). Withthis datasegmentation, sepa-rateseverity–frequencymodelsaredeveloped foreachaccident severitylevel.Inthisway,aseriesofnegativebinomialaccident frequencymodelsweredevelopedforeachcrashseveritylevelto predictthenumberofaccidentsateachseveritylevelonroadway segments.Unfortunately,suchanapproachcangeneratea statis-ticalprobleminthatinterdependenceduetolatentfactorslikely existsacrosscrashratesatdifferentseveritylevelsforaspecific roadwaysegment(Maet al.,2008).Forexample,anincreasein numberofaccidentsthatareclassifiedashavingacertainseverity levelisalsoassociatedwithchangesinthenumberofaccidents thatareclassifiedwithotherseveritylevels,settingupa correla-tionamongvariousinjury-outcomecrashfrequencymodels(Lord andMannering,2010).
Considerableresearchefforthasfocusedonmodelingaccident severityfromanindividualperspectiveusingsuch methodolog-icalapproaches aslogisticregression(e.g.,Luiet al.,1988;Yau, 2004),bivariatemodels(e.g.,Saccomannoetal.,1996;Yamamoto andShankar,2004),themultinomialandnestedlogitstructures toevaluateaccident-injuryseverities(e.g.,Shankar etal.,1996; Changand Mannering,1999;Carson and Mannering,2001;Lee andMannering,2002;UlfarssonandMannering,2004;Khorashadi etal.,2005),andthediscreteorderedprobitmodel(e.g.,O’Donnell and Connor, 1996; Duncan et al., 1998; Renski et al., 1999; Kockelmanand Kweon, 2002;Khattak etal., 2002; Kweonand Kockelman,2003;Abdel-Aty,2003).Formoredetailsonaccident severitymodelsmayrefertoSavolainenetal.(2011).
Although these models have been applied by a number of researcherswithaconsiderablesuccess,Miltonetal.(2008) indi-catedthatthesestudiesreliedheavilyondetaileddatainindividual accidentreportsandtheyhavebeenprovedtobedifficulttouse 0001-4575/$–seefrontmatter © 2012 Elsevier Ltd. All rights reserved.
insafetyprogrammingbecausealargenumberofevent-specific explanatoryvariables needto beestimated toproduceuseable severityforecasts. Moreover,significant contributory factors in the model are usually not closely related to traffic manage-mentstrategies,roadwaygeometrics,andweather-relatedfactors; therefore,thecorrespondingcountermeasuresaredifficultto pro-poseaccordingly.Furthermore,asdifferentdatascalesareusedby frequencymodelsandtheseveritymodel,integrationisextremely difficult.
Obviously,crashfrequency and severityaretwo key indices thatmeasureriskforaroadwaysegment.Eitheroneonly gener-atespartialinsightsforcrashrisk.Increasedscopeandin-depth insights cannot be obtained without considering both indices together.Thus,twopossibleintegratedmodelingapproacheswere attempted. The first approach uses a conventional frequency modeltopredicttotal numberof crashesand aseveritymodel, suchasthemultinomiallogitmodel,nestedlogitmodel,ordered probitmodel,ormixed logitmodel, topredictaggregate sever-ity probability (e.g., Yamamoto et al., 2008; Kim et al., 2008; Milton et al., 2008). However, the assumption that crash fre-quencyand severityare mutually independent still exists. The secondapproachappliesmultivariateregressionmodelsto pre-dictcrashfrequencies for differentseverity levels.Multivariate regressionmodelssimultaneouslydevelopcrashfrequency mod-elsbyseverity(Bijleveld,2005;MaandKockelman,2006;Song etal.,2006;ParkandLord,2007;Maetal.,2008;Aguero-Valverde andJovanis,2009;El-BasyounyandSayed,2009;Yeetal.,2009) toovercomethecorrelationproblemamongcrashfrequenciesat differentseveritylevels.However,thisapproachrequiresa com-plexestimation procedurecombinedwitha subjectivelypreset correlationmatrixofseveritylevels,makingfieldvalidationvery difficult.
Anotherdrawbackofthemultivariatemodelingapproachisits inabilitytograspassociatedchangesrelatedtoseverityand fre-quencyvariablesonly.Ifonefailstoobserveseparatelytheeffectsof factorscontributingtocrashfrequencyandseverity,the multivari-atemodelmaybepartlylimitedforpracticalprogramevaluation. Anappealingideaistoviewriskfactorsaccordingtotheiraccident descriptivecomponents(i.e.,severityandfrequency)individually under an integrated framework. However, expected difficulties arisewhenanalyzingsubjectsandprocedures.Consequently,using aconceptualmodelcombiningbothcrashfrequencyandseverity isworthwhile.
Thus, this paper aims to develop a novel multinomial gen-eralized Poisson (MGP) model to simultaneously model crash frequency(countdata)andseverity(ratiodata).Furthermore,the proposedmodelconsidersthesubstitutionpatternamong sever-itylevelsandconstructsasharederrorstructureasacorrelation matrixthrougherrorcomponentsspecifiedunderanintegrated modelframework.AcasestudyofTaiwanfreewaycrashdatais utilized to assess the applicabilityof theproposed model. The remainderofthispaperisorganizedasfollows.Section2presents theproposedMGPmodel.Section3addressesdatacollectionand descriptive statistics of theaccident datasetfor Taiwan’s No. 1 Freeway.Section4presentsmodelestimationresultsand compar-isons.Section5discussessafetyimplicationsbasedonestimation results.Section6givesconcludingremarksandsuggestionsto fur-therresearch.
2. Theproposedmodels
TheMGPmodelisanextensionofthemultinomial-Poisson(MP) regressionmodel(TerzaandWilson,1990).Inthecontextofcrash frequencyandseveritymodeling,weassumethataccidentscanbe classifiedintoafinitenumberofclustersaccordingtoseveritylevels
andthatthefrequencyofeachseveritylevelfollowsaconditional multinomialdistribution,whichisexpressedasfollows:
f
⎛
⎝
Y J j=1 yj=N⎞
⎠
= N! J j=1 yj j J j=1yj! (1)wheref(·)istheconditionalprobabilityofY;Y=[y1,y2,...yj,...,yJ]
and
Jj=1yj=N;yj=0,1,2,...,∞,forj=1,2,...,J,isarandomvector
representingtheobservedcrashcountsofsegmenttwithinagiven period(e.g.,1year)atseveritylevelj;Jisthetotalnumberof sever-itylevelsdeterminedinadvance; 1,2,...,Jaremultinomial
probabilitiesofseveritylevels1,2,...,J,respectively;j=yj/Nand
1+2+...+J=1;andNisthetotalnumberofaccidentsacross
differentseveritylevelsofsegmentmwithinagivenperiod.Thus, theconditionalmultinomialdistributioncanbeusedtodetermine crashfrequenciesatvariousseveritylevels,i.e.,y1,y2,...,yJ,given
totalnumberofaccidents,N.Furthermore,thejointprobabilityof thesecrashfrequenciesh(y1,y2,...,yJ)canbeexpressedasthe
productofconditionalprobabilityandmarginalprobability:
h(y1,y2,...,yJ)=f
⎛
⎝
Y J j=1 yj=N⎞
⎠
·g⎛
⎝
J j=1 yj=N⎞
⎠
(2) whereg(·)=gJj=1yj=N
isthemarginalprobabilityofcrash counts.TerzaandWilson(1990)assumedthatthemarginal (uncon-ditional)probabilityhasthefollowingPoissondistribution:
g(·)=Nexp(N!−) (3)
whereg(·)istheprobabilitythatNaccidentsoccurred,andisthe expectednumberofaccidents.Forestimationpurposes,isusually specifiedas
=exp(ˇX) (4)
whereXandˇarevectorsofexplanatoryvariablesandestimated parameters,respectively.Theformulationofthemultinomial Pois-son(MP)modelisthenderivedbysubstitutingEqs.(1)and(3)into Eq.(2).
The Poisson model assumes that variance equals mean. If observed data exhibit over-dispersion (under-dispersion), this assumptiondoesnot hold.Thisleadstoestimation inefficiency becauseinferencewasinvalidatedbyunreliableestimated stan-darderrors.Wecanrelaxthisassumptionusingthegeneralized Poisson(GP)model(Famoyeetal.,2004;Dissanayakeetal.,2009). Theprobabilityfunctionoftotalaccidentsatanysegment,N,can bewrittenasEq.(5): g(·)=
1+ N (1+N)N−1 N! exp −(1+N) 1+ (5) whereisthedispersionparameter.If>0,theGPmodel indi-catestheover-dispersionfeatureintheempiricaldata.If=0,the probabilityfunctiondegeneratedtothePoissonmodel.Incontrast, if<0,theGPmodeldenotestheunder-dispersionfeatureinthe empiricaldata.AllotherinvolvedargumentsassociatedwithEq. (5)areasdefinedpreviously.ThemeanandvarianceofNare rep-resentedbyEqs.(6)and(7),respectively:E(N|X)= (6)
V (N|X)=(1+)2 (7)
AccordingtoEq.(6),theprobabilityfunctioninEq.(5) degener-atesintotheoriginalPoissonmodelas=0.Hence,theGPmodelis ageneralizedPoissonmodel.InterestedreaderscanrefertoFamoye (1993)fordetailedproofs.Inaccordancewiththederivationby
TerzaandWilson(1990),formulationoftheMGPmodelcanbe derivedbysubstitutingEqs.(1)and(5)intoEq.(2)asfollows:
h(y1,y2,... yJ)=
J j=1 yj j J j=1yj!⎡
⎣
1+⎛
⎝
J j=1 yj⎞
⎠
⎤
⎦
J j=1yj−1 × 1+
J j=1yj exp
⎡
⎣
− 1+Jj=1yj 1+
⎤
⎦
(8) where=J
j=1jisexpectedtotalaccidents.j=jisexpected
crashcountatthejthseveritylevel.jistheprobabilityofseverity
levelj.
Weassumeprobabilitycanbedeterminedbythemultinomial logit(MNL)model: i= exp(si)
j j=1exp(sj) (9)
whereSj=Z+
v
jisalinearlyadditivefunctionformeasuringriskofseveritylevelj;Zisavectorofnon-randomexplanatoryvariables, suchasroadwaygeometrics,trafficfactors,landuse,andweather condition; isavectorofunknownparameters;
v
jisarandomerrorterm,whichweassumeisaGumbeldistributionacrossall observations(McFadden,1981).
Eq.(8) is a straightforwardequationfor integrating thetwo descriptive model components(i.e., thefrequency and severity model),andtheprobabilityofaccidentfrequencyatroadsegment yjistheweightedsumofcrashcountsofallseveritylevelsonthe
samesegmentoveraunittimespan.However,animportant prop-ertyoftheMNLmodelisitsindependencefromirrelevantalternate severityoutcomes.Thisindependencemaybeamajorconcernif somecrash-injuryseveritylevelsshareunobservedeffects.To over-comepartlysucharestriction,anestedlogit(NL)modelcangroup somepossiblelevelsthatshareunobservedeffectsintoconditional nests(KoppelmanandWen,1998).TheNLmodelpartitionsa sever-ityoutcomesetintoseveralnests,eachcontainingcorrelatedlevels. TheNLmodelcanbeexpressedas
i= exp(si/k)
j∈Bkexp(sj/k) k−1
L l=1
j∈Blexp(sj/l) l (10)
whereBkrepresentsnestk,whichisasubsetcontainingcorrelated
outcomeswithrespecttocrashseverity;(1−k)isacorrelation
measureofunobservedfactorswithinnestk;andkisintherange
of0–1.Asthevalueofkdecreases,thestrengthofthecorrelation
withinthenestincreases.Notably,kisalsocalledtheinclusive
valuerepresentingthedegreeofcorrelationamongalternate sever-itylevelswithinnestk.Ifk=1,theNLmodelbecomesanMNL
model.Ifkisequaltozero,perfectcorrelationisimpliedamong
theseveritylevelsinthenest,indicatingthattheprocessbywhich crashesresultinparticularseveritylevelsisdeterministic.
Sincerelatedstudies(Shankaretal.,1996;LeeandMannering, 2002;SavolainenandMannering,2007;Savolainenetal.,2011) have revealed that two nearer accident severitylevels suchas “propertydamageonly”and“possibleinjury”,or“disablinginjury” and“fatality”,maytendtohavestrongcorrelationsduetoordinal natureofcrashseveritydata.SuchproblemviolatedMNLmodel’s independenceofirrelevantalternatives(IIA)propertyresultedin biasedparameterestimates.Inthatcase,anNLmodelispreferred. Whenthenestedstructureexistsinj,theMGPmodelevolves
intoaflexiblenestedgeneralizedPoisson(NGP)model,solvingthe problemofsubstitutionpatternsamongseveritylevels.
BasedontheworkbyYeetal.(2009),specifyingapartialorfull errorcomponentsstructuremaybeaninnovativechoice compar-ingtotheformulationofcorrelationmatrix.Theerrorcomponents structureisconsideredintheexpectedfrequencyandseverity functionofthreeseveritylevelssj(j=1,2,3),whichincludefatality
(s1),injury(s2),andpropertydamageonly(s3).Inthisstudy,four
randomcoefficients(i)arespecifiedtothefrequencyfunction
andseverityfunctionsj(j=1,2,3)tomodelthefollowingpartial
covariancestructure:
=exp(ˇX+ε+1u) (11)
s1=Z+
v
1+2u (12)s2=Z+
v
2+3u (13)s3=Z+
v
3+4u (14)where uis anindependentrandomvariable,which is normally distributed;andjaretheircorrespondingcoefficientstobe
esti-mated. To simplifythenumber of estimatedparameters in the errorcomponentsstructure,j−1standard deviationparameters are identified by subjectively setting one parameter equals to 1. We assume ε and
v
j have Generalized Poisson and Gumbeldistributions,respectively.Thus,thecumulativeprobability func-tionsconditionalonthisrandomvariableh(y1,y2,...,yJ|u)are
expressedas h(y1,y2,... ,yJ|u)=
J j=1j(Z,u)yj J j=1yj!⎡
⎣
1+⎛
⎝
J j=1 yj⎞
⎠
⎤
⎦
J j=1yj−1 × (X,u) 1+(X,u)
J j=1yj exp
⎡
⎣
−(X,u) 1+Jj=1yj 1+(X,u)
⎤
⎦
(15) TodistinguishitfromEq.(8),Eq.(15)iscalledthe multino-mialgeneralizedPoisson modelwitherrorcomponents(EMGP). Theunconditionalcumulativeprobabilityfunctionoftherandom multinomialcan thenbederived byintegrating theconditional cumulativeprobabilityfunctionoverthedistributionaldomainof thespecifiedrandomvariable:H(y1,y2,...,yJ)=
h(y1,y2,...,yJ)r(u)du (16)
wherer(u)istheprobabilitydensityfunctionofu.Asthisintegral doesnothavea neatclosed-formexpression,theunconditional probabilityfunctionmaybeapproximatedbythefollowing sim-ulatedprobabilityfunctionHs(y
1,y2,...,yJ): Hs(y 1,y2,...,yJ)= 1 R R
r=1 h(y1,y2,...,yJ|ur) (17)The estimation procedureof the EMGP model typically fol-lows the simulation-based maximum likelihood method,using Haltondraws,whichhaveamoreefficientdistributionofdraws fornumericalintegrationthanpurelyrandomdraws(Bhat,2003; Train,2003).Inmanyempiricalsettings,thenumberofdrawsfor simulationis determinedaccordingtothenumberofestimated variables,thecomplexityofmodelspecification,andsamplesizes. Foraccuracypurposes,theestimationresultsofproposedmodels arepresentedfor200Haltondraws.Theestimatedparametersdo notvarymarkedlyoncethenumberofreplicationsexceeds150in theempiricalcase(seeTrain(2003)forfurthertechniquedetails andsimulationissues).
Table1
Descriptivestatisticsof124segments.
Variable Description Mean SE Min Max
Crashcounts
Y3 Propertydamageonly(PDO) 70.4 63.7 3.0 284.0
Y2 Injury 4.1 3.5 0.0 17.0
Y1 Fatality 0.5 0.8 0.0 4.0
N Total 75.1 65.4 6.0 290.0
Crashcountsperkm(=crashcounts/segmentlength)
Z3 PDOcrashesperkm 16.4 16.3 1.2 83.5
Z2 Injurycrashesperkm 0.8 0.6 0.0 2.8
Z1 Fatalcrashesperkm 0.1 0.2 0.0 1.5
N Totalcrashesperkm 17.3 16.6 2.2 85.3
Freewaygeometrics
GL Segmentlength(km) 5.9 4.4 0.8 22.4
GN Numberoflanes 2.6 0.6 2.0 4.0
GC Curvature(‰) 0.7 1.1 0.0 7.1
GU Maximumupwardslope(%) 1.3 2.1 0.0 13.7
GD Maximumdownwardslope(%) 1.2 1.4 0.0 5.2
GO Clothoidcurvevalue(thousanddegrees) 0.9 0.9 0.0 3.2 GS Speedlimit(GS=1for110km,GS=0else) 0.5 0.5 – – Rainfall
RF Annualrainfall(hundredmillimeters) 21.1 7.5 11.1 38.9 Averagedailytraffic
TTV Totaltraffic(thousandpassengercarunits) 69.2 28.7 10.8 157.0 PSV Percentageofsmallvehicles(%) 51.4 10.1 31.9 70.5
PLV Percentageoflargevehicles(%) 23.8 4.2 15.5 34.2
PKV Percentageoftrailer-tractors(%) 24.8 8.7 9.2 41.0 Freewayfacilities(dummyvariables,yes=1;no=0)
PT Presenceoftollstation 0.2 0.4 – –
PR Presenceofrestarea 0.1 0.3 – –
PS Presenceofpostedspeedcamera 0.3 0.5 – –
Neighborhood(dummyvariables,yes=1;no=0)
AM Adjacenttometropolitan 0.5 0.5 – –
AP Adjacenttoairport,seaportorindustryarea 0.2 0.4 – –
3. Data
TheaccidentdatasetforTaiwan’sNo.1Freewayin2005was
collected.Datawerefromthreesources:(1)theaccidentdatabase;
(2)geometricdocuments;and(3)thetrafficdatabase.The
acci-dentdatabase,maintainedbytheNationalHighwayPoliceBureau
(NHPB),containsaccidentinformation,suchascrashseverity,
loca-tionand timeofanaccident,andnumberand typesofvehicles
involved.Geometricdataweredigitalizedaccordingtotheofficial
as-constructedfreewaydrawings,includingnumberoflanes,slope,
curvaturedegree,andclothoidcurvevalue.
Taiwan’sNo. 1 Freeway runsnorth–south, is 373.3km long,
andhas63interchanges.Tofacilitatemodelestimation,astudy
segmentisformedbytwoadjacentinterchanges.Byconsidering
north-andsouth-bounddirectionsseparately,124analytical
sam-plesareobtained.Sincethelengthsofsegmentsremarkablydiffer,
tobetterreflectthecrashrisk,thedependentvariableispresented
bythecrashcountsdividedbythesegmentlength(GL).The
traf-ficdatabase,maintainedbytheNationalFreewayBureau(NFB),
includestrafficvolume,speedandoccupancyofthreevehicletypes
detectedbyloopdetectorsonabasicsegmentoron-ramp(small
vehicles,largevehiclesandtrailer-tractors).Consideringthe
val-uesofpassenger carequivalent(pce)of threetypesofvehicles,
thetotaltrafficateachroadsegmentaremeasuredinpassenger
carunits.Table1givesdescriptivestatisticsforthesesegments.
Themeanandstandarddeviationofaccidentsdifferineithertotal accidentcasesorthosecasesatvariousseveritylevels,suggesting thatthepotentialproblemofover-orunder-dispersionmaycause inefficientmodelestimationandbias.
Table2 presentsthecross-tabulationof crashfrequency and severity.Intotal,67(1%)fatalaccidentsoccurredin2005,and8735 (94%)accidentswereproperty-damage-onlyaccidents.Moreover,
all124segmentshad atleast onePDOaccident, whileonly 47 segments(38%)hadatleastonefatalaccident.
4. Results
AccordingtomodelformulationinSection2,fourpossible mod-elscanbeestimated:theMGPmodelwithorwithoutconsidering errorcomponents amongseverity levels,namely, theMGP and EMGPmodels.TwoNGPmodelsconsideringdifferentnested struc-tureamongseveritylevels,namely,theNGP1(nestingtwosevere severitylevels:fatalityandinjury)andNGP2(nestingtwominor severitylevels:PDOandinjury)aretested.Unfortunately, accord-ingtotheestimatedinclusivevaluesfortwoNGPmodels,wecould notfindanypossiblecorrelatednestingbetweentwosevere acci-dentlevels(i.e.,injuryandfatalitywitht-ratioofk=0.634)nor
twonon-severeaccidentlevels(i.e.,injuryandPDOwitht-ratioof k=0.299).
Tables 3and 4compare performance indicesand prediction accuracyamong models,respectively.InTable3,the goodness-of-fit indices, including number of significant variables, means and standard deviations of predicted accident counts, value, log-likelihoodvalues,adjustedrho-square,andtheBayesian infor-mationcriterion(BIC)arecompared.Theestimationresultsshow thatthemodelwiththeerrorcomponent(i.e.,theEMGPmodel) performbetterthanthosemodelsthatdonotconsidererror com-ponent(i.e.,theMGPandNGPmodels),andtwonestedmodelsdo notperformbetterthanthemultinomialmodels(i.e.,theMGPand EMGPmodels)intermsofBICvalues.Additionally,accordingto theestimateddispersionparameter()ofEMGP,whichis decreas-ingfrom0.082to0.062,theassociatedasymptoticallytstatistics aresignificantlydifferentfromzeroaswell,indicatingthat empir-ical data have a slightly over-dispersion problem. In addition,
Table2
Cross-tabulationofcrashfrequencyandseverity.
Severitylevel Totalcrash
PDO Injury Fatality
Numberofcrashes
Crashcounts 8735(94%) 509(5%) 67(1%) 9311(100%)
Crashcountsperkm 2038(95%) 96(4%) 13(1%) 2147(100%) Numberofsegments
Withatleastonesuchcrash 124(100%) 110(89%) 47(38%) Withoutanysuchcrash 0(0%) 14(11%) 77(62%)
Total 124(100%) 124(100%) 124(100%)
Table3
Comparisonsofgoodness-of-fitamongthemodels.
Models Goodnessoffit
Ka Crash(std.)b c LL(ˇ) Adj-2d BICe
MultinomialgeneralizedPoisson(MGP) 26 18.33(14.53) 0.082 −1108.130 0.147 2341.588
NestedgeneralizedPoisson(NGP1) 27 18.33(14.53) 0.082 −1108.095 0.147 2346.339
NestedgeneralizedPoisson(NGP2) 27 18.33(14.52) 0.082 −1106.496 0.148 2343.139
MultinomialgeneralizedPoissonwitherrorcomponents(EMGP) 29 16.39(12.76) 0.062 −1037.935 0.201 2215.659
aK:numberofsignificantvariablesunder˛=0.1level. bCrash:meanpredictedcrashcounts.
c :dispersionparameter.
d Adj-2:rho-squareadjustedincompassionwithNullmodel(withthreeconstantsforcrashseverityandasingleconstantforgeneralizedPoissonmodel). eBIC=−2×LL(ˇ)+K×LnN.
Table4
Comparisonsofpredictionaccuracyamongthemodels.
Severity Accuracy Model Actual
MGP NGP1 NGP2 EMGP Fatality Crash(%) 0.12(0.82%) 0.12(0.83%) 0.12(0.82%) 0.10(0.76%) 0.10(0.82%) MAPE 0.319 0.321 0.333 0.307 – RMSE 0.200 0.200 0.205 0.198 – Injury Crash(%) 1.06(7.48%) 1.06(7.48%) 1.06(7.49%) 0.90(7.38%) 0.78(7.48%) MAPE 0.816 0.816 0.814 0.695 – RMSE 0.746 0.746 0.748 0.654 – PDO Crash(%) 17.15(91.70%) 17.15(91.70%) 17.14(91.69%) 15.39(91.86%) 16.44(91.70%) MAPE 0.698 0.698 0.698 0.617 – RMSE 13.451 13.450 13.447 13.111 –
Note:Thepercentagesofthepredictedcrashcountsatthreeseveritylevelsaregiveninparentheses.
specifyingtheerrorcomponentcanmitigatevariationin.Hence,
theestimatedoftheEMGPmodelislowerthanthatoftheMGP
andtwoNGPmodels,buttheinclusionoferrorcomponentscould
notperfectlyresolvetheover-dispersionproblem.
Table4comparesthepredictionaccuracyofthefourmodels bymeanabsolutepercentageerror(MAPE)androot-mean-square error(RMSE).TheEMGPmodelperformsbestincomparisonwith othermodels,althoughallfourmodelsachieverelativelyhigh pre-dictionaccuracy(Table4).
Forsimplicity,onlyestimatedparametersoftwoextreme mod-elsare reportedand compared in Tables 5 and 6, respectively. Thisstudysets˛=0.10asthevariableselectioncriteriontoavoid an excessive number of non-stable and insignificant variables adverselyaffectingefficiencyincalculatingnumericalvaluesand convergenceresults.Therefore,thepotentialvariables,annual rain-fall(RF)andpercentageoftrailer-tractors(PKV),areremoveddue totheirinsignificanteffects.Thisstudyalsotestsallpossible rela-tionshipsamongvariables,includinglinear,squared,exponential, andnaturallogrelationships.
5. Discussions
Accordingtoestimation resultsof theMGPand EMGP mod-els(Tables5and6),allsignificantvariablesarealmostthesame
witha relatively similarmagnitudes;however, variables of the EMGPmodeltypicallyhavemoresignificanteffectsintermsofthe tstatistic,againdemonstrating thesuperiorperformance ofthe EMGPmodel.Thus,onlyestimationresultsoftheEMGPmodelare discussedbelow.
Onlytwovariablesofmaximumdownwardslope(GD)and adja-centtometropolitan(AM)havesignificanteffects onbothcrash frequencyandseverity,whileothervariablesofcrashfrequency andseveritymodelcomponentsarealldifferent,suggestingthat thefactorscontributingtocrashfrequencyandseveritydiffer.
First, in terms of geometric variables, maximum downward slope(GD)are significantlytestedin bothfrequencyand sever-itymodelcomponents,whilenumberoflanes(GN),exponentialof maximumupwardslope(GU),clothoidcurvevalue(GO),andspeed limit(GS)onlysignificantlycontributetocrashseverityand curva-ture(GC)onlyaffectcrashfrequency.TheGNreducesPDOcrashes butresultsintomoreseverecrashes,indicatingthatmorenumber oflanesmaycausesevereaccidents.Theexp(GU)hasanegative coefficientonfatalcrashesbecausedriverstendtodriveatalower speed onan upward-sloped segmentand then largelymitigate theseverityofcrashes.Contrarily,bothGDandGOhavepositive coefficientsassociatedwiththefatalandinjurycrashes,implying thecrashesathighdownward-slopedsegmentsandcurved transi-tioncurvesaremoresevere.TheGShasapositiveeffectoninjury
Table5
ModelresultsofthemultinomialgeneralizedPoisson(MGP).
Variable Severitylevel
Fatality Injury PDO
Para. t-Stat Para. t-Stat Para. t-Stat Logitcrashseveritymodelcomponent
Constant – 1.407 2.147 5.330 8.113
Freewaygeometrics
GN Numberoflanes – – −0.259 −4.053
Exp(GU) Exponentialofmaximumupwardslope −0.466 −2.097 – – GD Maximumdownwardslope 0.306 4.034 0.183 6.861 –
GO Clothoidparameter 0.250 2.341 0.177 4.158 –
GS Speedlimit – 0.280 3.017 –
Trafficcharacteristics
TTV Totaltraffic −0.709 −2.501 −0.424 −4.169 –
PLV Percentageoflargevehicles 4.604 5.755 4.604 5.755 – Neighborhood
AM Adjacenttometropolitan – – 0.271 3.276
Freewayfacilities
PS Presenceofpostedspeedcamera – −0.685 −2.880 −0.489 −2.175 PR Presenceofrestarea −1.361 −2.990 −0.321 −2.546 –
Variable Para. t-Stat
GeneralizedPoissoncrashfrequencymodelcomponent(forallseveritylevels)
Constant 1.237 3.465
0.082 8.407
Freewaygeometrics
GC Curvature 0.151 2.238
GD Maximumdownwardslope −0.555 −4.099
GD2 Squareofmaximumdownwardslope 0.054 1.876
Trafficcharacteristics
PSV Percentageofsmallvehicles 3.050 4.291
Neighborhood
AM Adjacenttometropolitan 0.504 3.442
AP Adjacenttoairport,seaportorindustryarea 0.498 2.565
PT Presenceoftollstation −0.419 −2.568
Goodnessoffitmeasures
Log-likelihood(Nullmodel) −1298.488 Log-likelihood(Fullmodel) −1108.130
Adj-2 0.147
Samples 124
Note:Nullmodel:withthreeconstantsforcrashseverity(marketshare)andasingleconstantforgeneralizedPoissonmodel.
crashesbecausedriverstendtoincrease theirspeedatthe
seg-mentswithahigherspeedlimit,increasingaccidentseverityonce
theaccidentoccurred.
TheGCaffectscrashfrequency,suggestingthatahighfreeway
curvaturecoefficientincreasesaccidentfrequency.TheGDhasa
polynomialeffect(anegativelineareffectandapositivesquared
effect)onaccidentfrequencyandalinearpositiveeffecton
acci-dentseverity(onlyforfatalityandinjury).Bytakingaderivative
termofa variable,a 1◦ increase inGD hasa marginal effectof
increasingcrashfrequencyby−0.448+0.072×GD,suggestingthat
aslightdownward slope mayreduceaccidentfrequency.
How-ever,onceaslope’sgradeexceeds6.22%,crashfrequencyincreases
rapidly,suggestingthatanabruptdownward slopesignificantly
contributes to a reduced number of PDO crashes and, in turn,
increasesaccidentseverity.Asslopeincreases,driverawareness
increases,reducingaccidentfrequencyforgentleslopes.However,
whenaslopeexceedsathreshold(6.22%inthisstudy),stopping
becomesincreasingly difficult,resultinginseverer accident
fre-quency.
Intermsoftrafficcharacteristics,theTTVhasnegativeeffectson
twosevereseveritylevels,implyingthecrashseveritycanbe
low-eredatthesegmentswithhightrafficflowbecauseoflowertravel
speedcausedbytrafficcongestion.However,thePLVhasrelatively
higheffectsontwoseverecrashes,suggestingthehigher
percent-ageoflargevehicles,themoresevereofthecrashes.Additionally,
thePSVhasapositiveeffectoncrashfrequency.Asthepercentage
ofsmallvehiclesincreases,thepercentageoflargevehiclesand
tractor-trailersisthendecreasedanddrivers’awarenessmaybe
reducedandtravelspeedisincreased,resultingintoahighcrash
potentialcondition.ThisresultissimilartothefindingsofHiselius
(2004)inSweden.
Thevariableofadjacenttometropolitan(AM)increasescrash frequencyandseverityforPDOonly,suggestingthatahighnumber ofaccidentsoccuronsegmentsclosetourbanareasand, fortu-nately,theseaccidentshavelowseverity.Thisis becausetraffic volumeonsegmentsneighboringurbanarterialsisusuallyheavy andvehiclestravelatarelativelyslowspeed,increasingthe poten-tialforPDOaccidents.Thevariableofadjacenttoairport,seaportor industrypark(AP)alsoincreasescrashfrequency.Itisbecausethere aremoretruckstravelingatthesegmentsnearairports,seaports andindustryparks,makingcrashpotentialhigh.
In terms of freeway facilities, posted speed cameras (PS) decreasethepotentialofnon-severecrashes(injuryandPDO)given thenumberofaccidentsunchanged,suggestingthatalthoughaPS
Table6
ModelresultsofmultinomialgeneralizedPoissonwitherrorcomponents(EMGP).
Severitylevel
Fatality Injury PDO
Para. t-Stat Para. t-Stat Para. t-Stat Logitcrashseveritymodelcomponent
Constant – 2.000 65.822 5.587 85.503
Freewaygeometrics
GN Numberoflanes – – −0.152 −6.421
exp(GU) Exponentialofmaximumupwardslope −0.496 −15.989 – – GD Maximumdownwardslope 0.342 11.068 0.185 6.316 –
GO Clothoidparameter 0.231 7.459 0.158 5.248 –
GS Speedlimit – 0.369 11.954 –
Trafficcharacteristics
TTV Totaltraffic −0.724 −23.387 −0.738 −25.559 – PLV Percentageoflargevehicles 6.488 89.411 6.488 89.411 – Neighborhood
AM Adjacenttometropolitan – – 0.200 6.447
Freewayfacilities
PS Presenceofpostedspeedcamera – −0.711 −22.936 −0.483 −15.604 PR Presenceofrestarea −1.382 −44.519 −0.579 −18.647 –
Errorcomponentincrashseveritymodel
S 1.000 – 0.262 8.459 0.824 26.527
Para. t-Stat
GeneralizedPoissoncrashfrequencymodelcomponent(forallseveritylevels)
Constant 0.982 31.684
0.062 6.390
Freewaygeometrics
GC Curvature 0.152 4.925
GD Maximumdownwardslope −0.448 −14.797
GD2 Squareofmaximumdownwardslope 0.036 3.352
Trafficcharacteristics
PSV Percentageofsmallvehicles 3.260 95.035
Neighborhood
AM Adjacenttometropolitan 0.428 13.763
AP Adjacenttoairport,seaportorindustryarea 0.534 17.217 Freewayfacilities
PT Presenceoftollstation −0.387 −12.458
Errorcomponentincrashfrequencymodel
GPM 0.246 7.923
Goodnessoffitmeasures
Log-likelihood(Nullmodel) −1298.488 Log-likelihood(Fullmodel) −1108.130
Adj-2 0.201
Samples 124
Note:Nullmodel:withthreeconstantsforcrashseverity(marketshare)andasingleconstantforgeneralizedPoissonmodel.
doesnotreducecrashfrequency,itmayincreasecrashseverity.The
causeandeffectrelationshipmaybereversed.Thatis,postedspeed
camerasareusuallyinstalledatthesegmentswithhighpotential
forfatalcrashes.Ifasegmenthasarestarea(PR),ithasaneffect
incontrasttothatofPS,becausemerginganddiverging
maneu-versonthesesegmentsslowtrafficdownandreducepotentialfor
severeaccidents.Meanwhile,ifthesegmenthasatollstation,the
frequencyofaccidentsisreduced.Driverswouldbemorecareful
whiletraversingtollstationsatalowerspeedduetomore
compli-cateddrivingmaneuversrequiredthantravelingatothersegments,
sothecrashpotentialismitigated.
Theestimatedparametersoftheexplanatoryvariablesin
pro-posedmodelresultsdo notdirectlyshowthemagnitudeofthe
effects ontheexpected frequencyfor each leveland all
severi-ties.Moreover,someexplanatoryvariables(i.e.,AMandGD)donot
carrythesameeffectsandimplicationsoncrashfrequencymodel
andseveritymodelcomponents,respectively.Tobetterunderstand
theimpactofcontributoryfactors,Table7furtherreportsthe
elas-ticityeffectsofsignificantvariables onindividualseveritylevels (i.e.,PDO,injuryandfatality)andonaggregatelevel.Since calcula-tionformulasandimplicationsofdummyvariablesandcontinuous variables aredifferent,theycannotbecomparedand shouldbe describedrespectively.
Aggregatelevelelasticityvalues forcontinuous variablesare computedbasedontheestimatedEMGPmodelbyEq.(18): tjk=
∂E(yjt) ∂xjtk xjtk E(yjt) (18) whereE(yjt)=jt(xjtk)jt(xjtk);E(yjt)isexpectedfrequencyofsever-ityleveljatsegmentt;andxjtkisthecontributoryvariablekof
acci-dentfrequencyatseverityleveljonsegmentt.Asxjtkhaschanged, the accident frequency and severity are adversely affected, such that elasticity represents the effect of the corresponding
Table7
AggregateelasticityestimatesoftheEMGPmodel.
Variable Severitylevel Frequency
Fatality Injury PDO Continuousvariable
Freewaygeometrics
GN Numberoflanes 0.383 0.377 −0.024 0.000
GC Curvature 0.243 0.142 0.147 0.147
GU Maximumupwardslope −0.098 0.001 0.001 0.000
GD Maximumdownwardslope 0.226 −0.081 −0.244 −0.232
GO Clothoidcurvevalue 0.208 0.132 −0.009 0.000
Trafficcharacteristics
TTV Totaltraffic −0.659 −0.671 0.043 0.000
PSV Percentageofsmallvehicles 1.820 1.757 1.887 1.880 PLV Percentageoflargevehicles 1.422 1.440 −0.093 0.000 Dummyvariable
Freewaygeometrics
GS Speedlimit −0.623 10.790 −0.626 0.000
Neighborhood
AM Adjacenttometropolitan −0.313 3.877 −0.478 −0.238
AP Adjacenttoairport,seaportorindustryarea 39.476 46.454 33.394 34.147 Freewayfacilities
PS Presenceofpostedspeedcamera 22.259 −9.784 0.430 0.000 PT Presenceoftollstation −22.654 −23.631 −23.710 −23.699
PR Presenceofrestarea −61.650 −35.320 2.456 0.000
factoroncrashfrequencyateachseveritylevel.Additionally,
“elas-ticityeffects”ofdummyvariablesarecomputedbyalteringthe
valueofthevariableto“1”forthesubsampleofobservedsegments
forwhichthevariabletakesavalueof“0”,andto“0”forthe
sub-sampleforwhichthevariabletakesavalueof“1”.Wethensumthe
shiftsofexpectedfrequenciesinthetwosubsamplesafter
revers-ingthesignoftheshiftsinthesecondsubsample,andcomputean
effectivepercentagechangeinexpectedaggregatefrequency.Thus,
thedummyelasticityeffectcouldbeinterpretedasthepercentage
changeattheexpectedfrequencyofaninjuryseverityleveldue
tochangeinthedummyvariablefrom0to1(formoredetailssee
EluruandBhat,2007).
Specifically,for continuousvariablesofPSV andPLV havean estimatedelasticity>1forsevereaccidenttypes,suggestingthat theyarekey factorstomoresevereaccidents.Accordingtothe estimationresultsoftheEMGPmodel(Table6),anincreaseinPSV significantlyincreasesthenumberofaccidentsbutnotcrash sever-ity.By elasticityestimates,PSV wasactuallyidentified asa key factorcontributingtocrashfrequencywiththesimilarmarginal effectsoneachseveritylevel.Itisworthofnotingthatcrashesat thesegmentswithhighheavytraffictendtobelesssevere.
Comparingtothehighelasticityeffectsoftrafficcharacteristics, geometricvariableshaverelativelylowereffectsoncrashseverity andfrequency.Itisbecausethegeometricdesignstandardfor free-waysisusuallyhigherthansurfaceroadways,makinghighlycurved andslopedfreewaysegmentsbarelyexisted.However,accordingto thecomputedelasticityeffects,somegeometricvariablesstillaffect crashseverityandfrequency.Generally,toocurvedandtoomany lanesfreewayshouldbeavoidedinfreewayplanninganddesign. Itisinterestingtonotethatthemaximumdownwardslopehave apositiveelasticityeffectonfatalcrashesbutanegativeelasticity effectoncrashfrequency,becausedriverswouldbemorecarefully whiletravelingatthedownwardslopedsegments,butonceacrash occurs,theseveritywouldbelargelyincreasedduetothedifficulty inbraking.
Theelasticityeffectsofdummyvariablesarerelativelylarger thanthoseofcontinuousvariablesbecauseoftheirdifferent formu-las.Therefore,itismeaninglesstocomparetheeffectsofcontinuous anddummyvariables.However,amongalldummyvariables,AP hasthelargestpositiveelasticityeffectsoncrashesatallseverity
levels.Toinstallwarningsignsandtoproperlyconfine overtak-ingbehaviorsatthesegmentsnearairports,seaportsandindustry parkscouldeffectivelyreducecrashesatallseveritylevels. Con-versely,PT andPR havenegativeeffects onseverecrashes.The presenceoftollstationandrestareacanslowvehiclespeedand reducethenumberofsevereaccidents.Notably,thepresenceof restareacanlargelyreducesevereaccidentsbutslightlyincreases PDOaccidents.
6. Conclusions
Thisstudycontributestoliteratureinseveralways.First,this studyintegratesanaccidentfrequencymodelwithaseveritymodel undertheMGParchitecture,andusestheintegratedmodelto ana-lyzeaccident data—countdata(crash frequency)and ratiodata (severity)—suchthattheMGPmodelismoreefficientin evaluat-ingandpresentingaccidentdata.Notably,accordingtoestimation results,thefactorscontributingtoaccidentfrequencyandseverity differmarkedly.Generally,trafficrelatedfactorshavelargereffects oncrashseverityandfrequencythangeometricfactors.
Additionally,four modelsaredeveloped and compared.This studyadoptedthesharederrortermtoconstructcommonerrors andcovariancestructuresoastoimprovemodelexplanatory capa-bilityandreliability.TheestimationresultsshowthattheEMGP modelperformsbest,asthismodelspecifiestheerrorcomponent inthecrashfrequencyandseveritymodelbyallowingdifferent errorsincrashfrequencyandseverity.Thus,theestimationresults showthattheproposedcovariancestructurecanfurtherenhance themodelperformance.
Basedontheproposedframework,futurestudiescanintroduce moreflexiblemodelsinthecontextoffrequencymodeling,such asPoissonlog-normal,random-parametersandothermixed dis-tributioncountmodels.Formodelingseverityoutcomes,ordered probit,mixedlogit(alsocalledtherandomparameterslogitmodel) andmorecompatiblegeneralizedextremevaluemodels(GEV fam-ilymodel)likegeneralizednestedlogit(GNL)arerecommended. Additionally,there is nosegmentwithzerocrashcountdueto thespatialsegmentationusedinthisstudy,whichmightleadto biasedestimationparameters.Morerefinedspatialsegmentation orothercensoredmodels(e.g.,TobitregressioninAnastasopoulos
etal.,2012)onaccidentratescanbeconsidered.Furthermore,this studyuses thesharederrorcomponent tohandlethe common errortermandcovariancestructure.Thecovariancestructurecan bederived toenhancemodelperformance further.Additionally, italsodeservestocomparepredictionperformancesamong dif-ferentmodelingframeworksinthecontextofcrashseverityand frequency,suchasmultivariatePoissonlog-normal(MPLN) mod-els,whichaimstosimultaneouslymodelingcrashfrequenciesat allseveritylevels.Last,additionalexplanatoryvariablescanbe uti-lizedtoinvestigatetheireffectsonaccidentfrequencyandseverity togeneratemoreeffectivesafetyimprovementstrategies.
Acknowledgements
Theauthorsareindebtedtothreeanonymousreviewersfortheir insightfulcommentsandconstructivesuggestions,whichhelp clar-ifyseveralpointsmadeintheoriginalmanuscript.Thisstudywas financiallysponsored bytheROCNationalScienceCouncil(NSC 97-2628-E-009-035-MY3).
References
Abdel-Aty,M.A.,Radwan, A.E.,2000.Modeling trafficaccidentoccurrenceand involvement.AccidentAnalysisandPrevention32(5),633–642.
Abdel-Aty,M.,2003.Analysisofdriverinjuryseveritylevelsatmultiplelocations usingorderedprobitmodels.JournalofSafetyResearch34(5),597–603. Aguero-Valverde,J.,Jovanis,P.P.,2009.BayesianmultivariatePoissonlog-normal
modelsforcrashseveritymodelingandsiteranking.In:Presentedatthe88th AnnualMeetingoftheTransportationResearchBoard.
Anastasopoulos,P., Mannering,F.,2009.Anoteonmodeling vehicle-accident frequencieswithrandom-parameterscountmodels.AccidentAnalysisand Pre-vention41(1),153–159.
Anastasopoulos,P.,Mannering,F.,Shanker,V.,Haddock,J.,2012.Astudyoffactors affectinghighwayaccidentratesusingtherandom-parametersTobitmodel. AccidentAnalysisandPrevention45(1),628–633.
Bhat,C.,2003.Simulationestimationofmixeddiscretechoicemodelsusing ran-domizedandscrambledHaltonsequences.TransportationResearchPartB37 (1),837–855.
Bijleveld,F.D.,2005.Thecovariancebetweenthenumberofaccidentsandthe num-berofvictimsinmultivariateanalysisofaccidentrelatedoutcomes.Accident AnalysisandPrevention37(4),591–600.
Carson,J.,Mannering,F.,2001.Theeffectoficewarningsignsonaccidentfrequencies andseverities.AccidentAnalysisandPrevention33(1),99–109.
Chang,L.Y.,Mannering,F.,1999.Analysisofinjuryseverityandvehicleoccupancy intruckandnon-truck-involvedaccident.AccidentAnalysisandPrevention31 (4),579–592.
Dissanayake,D.,Aryaijab,J.,Wedagamac,P.,2009.Modellingtheeffectsofland useandtemporalfactorsonchildpedestriancasualties.AccidentAnalysisand Prevention41(4),1016–1024.
Duncan,C.,Khattak,A.,Council,F.,1998.Applyingtheorderedprobitmodeltoinjury severityintruck-passengercarrear-endcollisions.TransportationResearch Record1635,63–71.
El-Basyouny, K.,Sayed, T., 2009. Collisionprediction models using multivari-atePoisson-lognormalregression.AccidentAnalysisandPrevention41(4), 820–828.
Eluru,N.,Bhat,C.,2007.Ajointeconometricanalysisofseatbeltuseand crash-relatedinjuryseverity.AccidentAnalysisPrevention39,1037–1049. Famoye,F.,1993.RestrictedgeneralizedPoissonregressionmodel.Communications
inStatistics,TheoryandMethods22,1335–1354.
Famoye,F.,Wulu,J.T.,Singh,K.P.,2004.OnthegeneralizedPoissonregressionmodel withanapplicationtoaccidentdata.JournalofDataScience2,287–295. Hadi,M.A.,Aruldhas,J.,Chow,L.F.,Wattleworth,J.A.,1995.Estimatingsafetyeffects
ofcross-sectiondesignforvarioushighwaytypesusingnegativebinomial regression.TransportationResearchRecord1500,169–177.
Hiselius,L.W.,2004.Estimatingtherelationshipbetweenaccidentfrequencyand homogeneousandinhomogeneoustrafficflows.AccidentAnalysisPrevention 36,985–992.
Jones,B.,Janssen,L.,Mannering,F.,1991.Analysisofthefrequencyanddurationof freewayaccidentsinSeattle.AccidentAnalysisandPrevention23(2),239–255. Khattak,A.,Pawlovich,M.,Souleyrette,R.,Hallmark,S.,2002.Factorsrelatedtomore severeolderdrivertrafficcrashinjuries.JournalofTransportationEngineering 128(3),243–249.
Khorashadi, A., Niemeier,D.,Shankar,V., Mannering,F., 2005. Differencesin ruralandurbandriver-injuryseveritiesinaccidentsinvolvinglarge-trucks:an exploratoryanalysis.AccidentAnalysisandPrevention37(5),910–921. Kim,J.K.,Ulfarsson,G.,Shankar,V.,Kim,S.,2008.Ageandpedestrianinjuryseverity
inmotor-vehiclecrashes:aheteroskedasticlogitanalysis.AccidentAnalysisand Prevention40(5),1695–1702.
Kockelman,K.M.,Kweon,Y.J.,2002.Driverinjuryseverity:anapplicationifordered probitmodels.AccidentAnalysisandPrevention34(3),313–321.
Koppelman,F.S.,Wen,C.,1998.Alternativenestedlogitmodels:structure,properties andestimation.TransportationResearchPartB32(5),289–298.
Kweon,Y.,Kockelman,K.,2003.Overallinjuryrisktodifferentdrivers:combining exposure,frequency,andseveritymodels.AccidentAnalysisandPrevention35 (4),441–450.
Lee,J.,Mannering,F.,2002.Impactofroadsidefeaturesonthefrequencyand sever-ityofrun-off-roadwayaccidents:anempiricalanalysis.AccidentAnalysisand Prevention34(2),149–161.
Lord,D.,2006.ModelingmotorvehiclecrashesusingPoisson-gammamodels: exam-iningtheeffectsoflowsamplemeanvaluesandsmallsamplesizeonthe estimationofthefixeddispersionparameter.AccidentAnalysisandPrevention 38(4),751–766.
Lord,D.,Miranda-Moreno,L.F.,2008.Effectsoflowsamplemeanvaluesandsmall samplesizeontheestimationofthefixeddispersionparameterof Poisson-gammamodelsformodelingmotorvehiclecrashes:aBayesianperspective. SafetyScience46(5),751–770.
Lord,D.,Mannering,F.,2010.Thestatisticalanalysisofcrash-frequencydata:a reviewandassessmentofmethodologicalalternatives.TransportationResearch PartA:PolicyandPractice44(5),291–305.
Lui,K.,McGee,D.,Rhodes,P.,Pollock,D.,1988.Anapplicationofaconditional logisticregressiontostudytheeffectsofsafetybelts,principalimpactpoints, and car weights on drivers’ fatalities. Journal of Safety Research 19 (4), 197–203.
Ma,J.,Kockelman,K.M.,2006.BayesianmultivariatePoissonregressionformodels ofinjurycountbyseverity.TransportationResearchRecord1950,24–34. Ma,J.,Kockelman,K.M.,Damien,P.,2008.AmultivariatePoisson-lognormal
regres-sionmodelforpredictionofcrashcountsbyseverity,usingBayesianmethods. AccidentAnalysisandPrevention40(3),964–975.
Malyshkina,N.,Mannering,F.,2010.Empiricalassessmentoftheimpactofhighway designexceptionsonthefrequencyandseverityofvehicleaccidents.Accident AnalysisandPrevention42(1),131–139.
McFadden,D.,1981.Econometricmodelsofprobabilisticchoice.In:Manski,C.F., McFadden,D.(Eds.),StructureAnalysisofDiscreteDatawithEconometric Appli-cations.MITPress,Cambridge,MA.
Miaou,S.P.,Bligh,R.P.,Lord,D.,2005.Developingmedianbarrierinstallation guide-lines:abenefit/costanalysisusingTexasdata.TransportationResearchRecord 1904,3–19.
Miaou,S.P.,1994.Therelationshipbetweentruckaccidentsandgeometricdesignof roadsections:Poissonversusnegativebinomialregressions.AccidentAnalysis andPrevention26(4),471–482.
Milton,J.,Mannering,F.,1998.Therelationshipamonghighwaygeometrics,traffic relatedelementsandmotorvehicleaccidentfrequencies.Transportation25(4), 395–413.
Milton,J.,Shankar,V.,Mannering,F.,2008.Highwayaccidentseveritiesandthe mixedlogitmodel:anexploratoryempiricalanalysis.AccidentAnalysisand Prevention40(1),260–266.
O’Donnell,C.J.,Connor,D.H.,1996.Predictingtheseverityofmotorvehicle acci-dentinjuriesusingmodelsoforderedmultiplechoice.AccidentAnalysisand Prevention28(6),739–753.
Oh,J.,Washington,S.P.,Nam,D.,2006.Accidentpredictionmodelfor railway-highwayinterfaces.AccidentAnalysisandPrevention38(6),346–356. Park,B.J.,Lord,D.,2009.Applicationoffinitemixturemodelsforvehiclecrashdata
analysis.AccidentAnalysisandPrevention41(4),683–691.
Park,E.S.,Lord,D.,2007.MultivariatePoisson-lognormalmodelsforjointlymodeling crashfrequencybyseverity.TransportationResearchRecord2019,1–6. Poch,M.,Mannering,F.,1996.Negativebinomialanalysisofintersection-accident
frequencies.JournalofTransportationEngineering122(2),105–113. Renski,H.,Khattak,A.,Council,F.,1999.Effectofspeedlimitincreasesoncrash
injuryseverity:analysisofsingle-vehiclecrashesonNorthCarolinainterstate highways.TransportationResearchRecord1665,100–108.
Saccomanno,F.,Nassar,S.,Shortreed,J.,1996.Reliabilityofstatisticalroadaccident injuryseveritymodels.TransportationResearchRecord1542,14–23. Shankar,V.,Mannering,F.,Barfield,W.,1995.Effectofroadwaygeometricsand
environmentalfactorsonruralaccidentfrequencies.AccidentAnalysisand Pre-vention27(3),371–389.
Shankar,V.,Mannering,F.,Barfield,W.,1996.Statisticalanalysisofaccidentseverity onruralfreeways.AccidentAnalysisandPrevention28(3),391–741. Shankar,V., Milton,J.,Mannering,F.,1997. Modelingaccidentfrequencies as
zero-alteredprobabilityprocesses:anempiricalinquiry.AccidentAnalysisand Prevention29(6),829–837.
Savolainen,P.,Mannering,F.,2007.Probabilisticmodelsofmotorcyclists’injury severitiesinsingle-andmulti-vehiclecrashes.AccidentAnalysisandPrevention 39(6),955–963.
Savolainen,P.,Mannering,F.,Lord,D.,Quddus,M.,2011.Thestatisticalanalysisof highwaycrash-injuryseverities:areviewandassessmentofmethodological alternatives.AccidentAnalysisandPrevention43(5),1666–1676.
Song,J.J.,Ghosh,M.,Miaou,S.,Mallick,B.,2006.Bayesianmultivariatespatial mod-elsforroadwaytrafficcrashmapping.JournalofMultivariateAnalysis97(1), 246–273.
Terza,J.V.,Wilson,P.W.,1990.Analyzingfrequenciesofseveraltypesofevents:a mixedmultinomial-Poissonapproach.TheReviewofEconomicsandStatistics 72(1),108–115.
Train,K.,2003.DiscreteChoiceMethodswithSimulation.CambridgeUniversity Press,Cambridge,UK.
Ulfarsson,G.F.,Mannering,F.,2004.Differencesinmaleandfemaleinjuryseverities insport-utilityvehicle,pickupandpassengercaraccidents.AccidentAnalysis andPrevention36(1),135–147.
Wang,X.,Abdel-Aty,M.,2008.Modelingleft-turncrashoccurrenceatsignalized intersectionsbyconflictingpatterns.AccidentAnalysisandPrevention40(1), 76–88.
Yamamoto,T.,Shankar,V.,2004.Bivariateordered-responseprobitmodelofdriver’s andpassenger’sinjuryseveritiesincollisionswithfixedobject.Accident Anal-ysisandPrevention36(5),869–876.
Yau, K., 2004. Risk factors affecting the severity of single vehicle traf-fic accidents in Hong Kong. Accident Analysis and Prevention 36 (3), 333–340.
Yamamoto,T.,Hashiji,J.,Shankar,V.,2008.Underreportingintrafficaccidentdata, biasinparametersandthestructureofinjuryseveritymodels.AccidentAnalysis andPrevention40(4),1320–1329.
Ye,X.,Pendyala,R.M.,Washington,S.P.,Konduri,K.,Oh,J.,2009.Asimultaneous equationsmodelofcrashfrequencybycollisiontypeforruralintersections. SafetyScience47(3),443–452.