Abstract
This paper considers the statistical evaluation of DNA mixtures in the following situations: (1) two unknown contributors are related respectively to two typed persons, (2) two of the unknown or untyped contributors are related and the third unknown contributor is related to a typed person, or (3) there are two pairs of related unknown contributors to the DNA mixture. The corresponding formulas for evaluating the likelihood ratios on the strength of DNA evidence are derived and the kinship coefficients for the related persons are incorporated into the calculations. Two examples are analyzed for illustration.
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Acknowledgements
We thank the referees for helpful comments that improved the presentation of the paper. This work was partially supported by the Hong Kong RGC Competitive Earmarked Research Grant HKU 7022/04P, and the National Natural Science Foundation of China (10329102).
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Appendix
Appendix
Lemma 1
If the kinship coefficients of two individuals X1 and X2 are (k0,2k1,k2), then for any set of alleles D
where χ1 and χ2 are the genetic profiles of X1 and X2 respectively.
Proof
They are just Eqs. 4 and 5 in Hu and Fung (2003).
Lemma 2
For any U⊂M, and any pairwise distinct alleles a,b,c,d,∈U,
Proof
It is sufficient to note that \(I_{D} (a) = 1 \Leftrightarrow a \in D \Leftrightarrow (M \setminus U) \cup \{ a\} \subset D \subset M \Leftrightarrow M \setminus (U \setminus \{ a\} ) \subset D \subset M\), so
Thus Eq. 12 follows immediately from Eq. 3.
Similarly, \(I_{D} (a)I_{D} (b) = 1 \Leftrightarrow a,b \in D \Leftrightarrow (M \setminus U) \cup \{ a,b\} \subset D \subset M \Leftrightarrow M \setminus (U \setminus \{ a,b\} ) \subset D \subset M\). So Eq. 13 holds by Eq. 3.\(I_{D} (a)I_{D} (b)I_{D} (c) = 1 \Leftrightarrow a,b,c \in D \Leftrightarrow (M \setminus U) \cup \{ a,b,c\} \subset D \subset M \Leftrightarrow M \setminus (U \setminus \{ a,b,c\} ) \subset D \subset M\), so Eq. 14 holds by Eq. 3.\(I_{D} (a)I_{D} (b)I_{D} (c)I_{D} (d) = 1 \Leftrightarrow a,b,c,d \in D \Leftrightarrow (M \setminus U) \cup \{ a,b,c,d\} \subset D \subset M \Leftrightarrow M \setminus (U \setminus \{ a,b,c,d\} ) \subset D \subset M\), so Eq. 15 holds by Eq. 3.
Lemma 3
For any U⊂M, and any alleles a,b,c,d, we have
Proof
If a∉M, then both sides of Eq. 16 are zero; if a∈M∖U, then Eq. 16 is just Eq. 3; if a∈U, then Eq. 16 is just Eq. 12. Thus, Eq. 16 holds.
If a=b, then Eq. 17 is just Eq. 16. Next, we consider a≠b. If a or b is not in M, then both sides of Eq. 17 are zero; if a,b, ∈U, then Eq. 17 is just Eq. 13; if a∈U and b∈M∖U, then Eq. 17 is just Eq. 16; if a,b∈M∖U, then Eq. 17 is just Eq. 3. Thus, we have Eq. 17 by the symmetry of a and b.
If two of a,b,c, are identical, then Eq. 18 is just Eq. 17. So we consider that a,b and c are pairwise distinct. If one of a,b, and c is not in M, then both sides of Eq. 18 are zero; if a,b,c∈U, then Eq. 18 is just Eq. 14; if a,b,∈U and c∈M∖U, then Eq. 18 is just Eq. 17; if a ∈U and b,c∈M∖U, then Eq. 18 is just Eq. 16; if a,b,c ∈M∖U, then Eq. 18 is just Eq. 3. By the symmetry of a,b and c, Eq. 18 is hence proved.
If two of a,b,c and d are identical, then Eq. 19 is just Eq. 18. So we assume a,b,c and d are pairwise distinct. If one of a,b,c and d is not in M, then both sides of Eq. 19 are zero; if a,b,c,d∈U, then Eq. 19 is just Eq. 15; if a,b,c,∈U and d∈M∖U, then Eq. 19 is just Eq. 18; if a,b,∈U and c,d∈M∖U, then Eq. 19 is just Eq. 17; if a∈U and b,c,d∈M∖U, then Eq. 19 is just Eq. 16; if a,b,c,d∈M∖U, then Eq. 19 is just Eq. 3. Thus we prove Eq. 19 by the symmetry of a, b, c and d.
Proof of Eq. 5
Under the hypothesis declared in Eq. 4, the only related individuals are X1 and T1, and X2 and T2. Let χ1, χ2, and χ0 be the genetic profiles of X1, X2, and the other x−2 unknown contributors, respectively, then we have χ=χ1⋃χ2⋃χ0 and further by Eq. 2
Using Eq. 11 for the first two items in Eq. 20, \(P({\mathop \chi \nolimits_0 } \subset D) = ({\sum\nolimits_{i \in D} }\,p_{i} )^{{2(x - 2)}}\), and the results of Lemma 3, we can have Eq. 5 from Eq. 1 after some matrix manipulation.
Proof of Eq. 7
Under hypothesis declared in Eq. 6, the only related individuals are X1 and T1, and X2 and X3. Let χ1, χ2, χ3, and χ0 be the genetic profiles of X1, X2, X3, and the other x−3 unknown contributors, respectively, then we have χ=χ1⋃χ2⋃χ3⋃χ0 and further by Eq. 2
Substituting Eqs. 10, 11, and \(P({\mathop \chi \nolimits_0 } \subset D) = ({\sum\nolimits_{i \in D} }\,p_{i} )^{{2(x - 3)}}\) into the expression of W(D) in Eq. 21 and then using Lemma 3, we can have Eq. 7 from Eq. 1 after some matrix manipulation.
Proof of Eq. 9
Under the hypothesis declared in Eq. 8, the only related individuals are X1 and X2, and X3 and X4. Let χ1, χ2, χ3, χ4, and χ0 be the genetic profiles of X1, X2, X3, X4, and the other x−4 unknown contributors, respectively, then we have χ=χ1⋃χ2⋃χ3⋃χ4⋃χ0 and further by Eq. 2
Substituting Eq. 10 and \(P({\mathop \chi \nolimits_0 } \subset D) = ({\sum\nolimits_{i \in D} }\,p_{i} )^{{2(x - 4)}}\) into Eq. 22 and then using Lemma 3, we have Eq. 9 from Eq. 1 after some matrix manipulation.
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Hu, YQ., Fung, W.K. Evaluation of DNA mixtures involving two pairs of relatives. Int J Legal Med 119, 251–259 (2005). https://doi.org/10.1007/s00414-004-0493-9
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DOI: https://doi.org/10.1007/s00414-004-0493-9