forensic dna inference icfis 2008 lausanne, switzerland mark w perlin, phd, md, phd joseph b kadane,...

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Forensic DNA Inference ICFIS 2008 ICFIS 2008 Lausanne, Switzerland Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008 Cybergenetics © 2003-2008

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Page 1: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Forensic DNA Inference

ICFIS 2008ICFIS 2008Lausanne, SwitzerlandLausanne, Switzerland

Mark W Perlin, PhD, MD, PhDMark W Perlin, PhD, MD, PhDJoseph B Kadane, PhDJoseph B Kadane, PhDRobin W Cotton, PhDRobin W Cotton, PhD

Cybergenetics © 2003-2008Cybergenetics © 2003-2008

Page 2: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Likelihood Ratio

quantitative rarity statistic in forensic science

match likelihood ratio (MLR)

posterior probability

Pr X =x|d{ }

match

data likelihood ratio (DLR)

data data likelihood

likelihood ratio

Pr d | X =x{ }

ratio

Page 3: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Match

itemquestionedevidence suspect

M Q,S( ) : for some value x∈X                     Q=x & S=x

data dQ dS

type Q S

Page 4: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Match Probabilityfor  uncertain  type Q, Pr Q =x{ } =q x( )

for  uncertain  type S, Pr S =x{ } =s x( )

= q x( ) ⋅s x( )x∈X∑

Pr M Q,S( ){ } = Pr Q=x & S=x{ }x∈X∑ (disjoint values)

= Pr Q = x{ } ⋅Pr S = x{ }x∈X∑ (assume types

independent)

Page 5: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Inner Product

Pr M Q,S( ){ } = q x( )⋅s x( )x∈X∑

• standard pattern comparison method

• widely used, powerful math properties

Pr M Q,S( ){ } = q x( )⋅s x( )dxX∫

Pr M Q,S( ){ } = q x( )⋅s x( )⋅μ x( )dxX∫

Page 6: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Match Rarityfor  random  type R, Pr R =x{ } =r x( )

MLR ≡Pr M Q,S( ){ }Pr M Q,R( ){ }

Define the Match Likelihood Ratio (MLR) statistic

Page 7: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

How to compute the MLR

MLR =Pr M Q,S( ){ }Pr M Q,R( ){ }

=q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

Page 8: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

MLR is a likelihood ratio

Hypothesis C: suspect S contributed to evidence item Q

Pr M |C{ } =Pr M Q,S( ){ }

MLR assesses match observation M under alternative contributor hypotheses C and C'

MLR =Pr M Q,S( ){ }Pr M Q,R( ){ }

=Pr M |C{ }Pr M |C{ }

Pr M |C{ } =Pr M Q,R( ){ }

Page 9: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

How to report a MLR

MLR =Pr M Q,S( ){ }Pr M Q,R( ){ }

The probability of a match between evidence type Q and suspect type S is (some number) times more likely than the probability of a match between evidence type Q and a random type R.

Page 10: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Type Probability

q x( ) =Pr Q=x|dQ{ }

∝ Pr dQ |Q=x{ } ⋅Pr Q=x{ }

likelihood function prior probability

posterior probability

Page 11: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Single Source DNA

Pr dQ |Q =x{ } =1 x=x0

0 otherwise⎧⎨⎩

Pr Q =x{ } ∝1

q x( ) ∝ Pr dQ |Q=x{ } ⋅Pr Q=x{ }

MLR =q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

=1

r x0( )

likelihood

prior

posterior

Page 12: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

DNA Mixture: Inclusion

Pr dQ |Q =x{ } =1 alleles x( )⊂alleles dQ( )

0 otherwise

⎧⎨⎪

⎩⎪

Pr Q =x{ } ∝1

q x( ) ∝ Pr dQ |Q=x{ } ⋅Pr Q=x{ }

MLR =q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

=1r x( )

x∈I∑

Page 13: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

DNA Inclusion Example

21

Perpetrator [1 1], [1 2], [2 2]Suspect [2 2]

MLR =q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

=

13⋅s x( )

x∈I∑

13⋅r x( )

x∈I∑

=

13⋅1

13⋅ p1

2 + 2p1p2 + p22( )

=1

p12 + 2p1p2 + p2

2

Page 14: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

DNA Mixture: Equality

Pr dQ |Q =x,V =y{ } =1 alleles x( )∪alleles y( ) =alleles dQ( )

0 otherwise

⎧⎨⎪

⎩⎪

Pr Q =x{ } ∝1

q x( ) ∝ Pr dQ |Q=x,V =y{ } ⋅Pr Q=x{ }

MLR =q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

=1r x( )

x∈J∑

Page 15: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

DNA Equality Example

21

Victim [1 1]Perpetrator [1 2], [2 2]Suspect [2 2]

MLR =q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

=

12⋅s x( )

x∈I∑

12⋅r x( )

x∈I∑

=

12⋅1

12⋅2p1p2 + p2

2( )

=1

2p1p2 + p22

(obligate allele)

Page 16: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Suspect Sgenotypeprobability

MLR

Evidence Q genotype prior probability

DLR

Constant Prior

OneGenotype

DLR is a special case of MLR

Mixture: Evidence Q 0/1 likelihood function

Page 17: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

DNA Mixture: Quantitative

Pr dQ |Q =x,V =y{ } =N wx+ (1−w)y[ ] ⋅u,Σ( )

Pr Q =x{ } =r x( ) 

q x( ) ∝ Pr dQ |Q=x,V =y{ } ⋅Pr Q=x{ }

MLR =q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

1, 2 & 3 unknownlow copy numberdamaged DNAcase-to-casemethod validation

Page 18: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

DNA Kinship

s x( ) ∝ Pr dS |S=x,W=w{ } ⋅Pr S=x|F =y,M =z{ }

MLR =q x( )⋅s x( )

x∈X∑

q x( )⋅r x( )x∈X∑

missing personspaternityfamilial searchmass disaster

Pr S =x|F =y,M =z{ } 

Pr dS | S =x,W=w{ }S

F M

W

1 2

Page 19: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Population SubstructureGenotypes are not independent: shared ancestry

Coancestry coefficient : allele IBD probability

Induces a measure on joint genotypes

MLR =q x( )⋅s x( )⋅μ θ,x( )

x∈X∑

q x( )⋅r x( )⋅μ θ,x( )x∈X∑

Page 20: Forensic DNA Inference ICFIS 2008 Lausanne, Switzerland Mark W Perlin, PhD, MD, PhD Joseph B Kadane, PhD Robin W Cotton, PhD Cybergenetics © 2003-2008

Conclusions

• introduced MLR: "match likelihood ratio"• an inner product ratio statistic• agrees with "data likelihood" DNA LR• extends LR to other DNA applications• statistical framework for non-DNA forensics