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DOI in the printed bibliography is fragmented by whitespace or line breaks. A longer candidate (10.1145/3805689.3812417VII) was visible in the surrounding text but could not be confirmed against doi.org as printed.
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J. Monnier, T. George, F. Guyard, C. Tarnec, and M. Kountouris, “Beyond base metric: The critical and overlooked role of meta-metrics in intersectional fairness,” in2026 ACM Conference on Fairness Accountability and Transparency, ser. FAccT ’26. ACM, 2026. [Online]. Available: https://doi.org/10.1145/3805689.3812417 VII. APPENDIX A. Proofs of equivalence between fairness notions and MI- Fair formulation Proof: (Statistical Parity)Suppose that we have I(A; ˆY) =0. Then, assumingP(A)̸=0:P(A; ˆY) =P( ˆY)P(A) ⇔P( ˆY|A)P(A) =P( ˆY)P(A)⇔P( ˆY|A) =P( ˆY)and ∀(a1,a 2)∈A 2,P( ˆY|A=a 1) =P( ˆY|A=a 2) =P( ˆY). In particular, when demographic groups are defined in binary terms, we haveP( ˆY|A=1) =P( ˆY|A=0). Proof: (Equal Opportunity)Suppose that we have IY=1 (A; ˆY) =0. Then, assumingP Y=1 (A)̸=0, we have PY=1 (A; ˆY) =P Y=1 (A)PY=1 ( ˆY)⇔P Y=1 ( ˆY|A) =P Y=1 ( ˆY) and∀(a 1,a 2)∈A 2, PY=1 ( ˆY|A=a 1) =PY=1 ( ˆY|A=a 2) ⇔ PY=1 ( ˆY;A=a 1) PY=1 (A=a 1) = PY=1 ( ˆY;A=a 2) PY=1 (A=a 2) ⇔ P( ˆY;Y=1;A=a 1) P(Y=1;A=a 1) = P( ˆY;Y=1;A=a 2) P(Y=1;A=a 2) ⇔P( ˆY|Y=1;A=a 1) =P( ˆY|Y=1;A=a 2) ⇒P( ˆY=1|Y=1;A=a 1) =P( ˆY=1|Y=1;A=a 2). In particular, when demographic groups are defined in binary terms:P( ˆY=1|Y=1;A=1) =P( ˆY=1|Y=1;A=0). Proof: (Predictive Equality)Following the same rea- soning as for Equal Opportunity, suppose that we have IY=1 (A; ˆY) =0. Then,∀(a 1,a 2)∈A 2,P( ˆY=1|Y=0;A= a1) =P( ˆY=1|Y=0;A=a 2). In particular, when demo- graphic groups are defined in binary terms:P( ˆY=1|Y= 0;A=1) =
Evidence payload
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"reconstructed_doi": "10.1145/3805689.3812417VII",
"ref_index": 32,
"resolved_title": null,
"verdict_class": "incontrovertible"
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